European Review of Agricultural Economics, Volume 45 (4) – Sep 1, 2018

/lp/ou_press/determinants-of-downside-risk-exposure-of-dairy-farms-u9u3YlGXjk

- Publisher
- Oxford University Press
- Copyright
- © Oxford University Press and Foundation for the European Review of Agricultural Economics 2018; all rights reserved. For permissions, please e-mail: journals.permissions@oup.com
- ISSN
- 0165-1587
- eISSN
- 1464-3618
- D.O.I.
- 10.1093/erae/jby012
- Publisher site
- See Article on Publisher Site

Abstract We investigate determinants of dairy producers’ risk exposure using a unique combination of foci on (i) downside risks, (ii) a holistic representation of revenues from milk and animal sales, (iii) climatic extremes and (iv) the role of animal health. A sample of German dairy farms reveals that animal health and heat stress indicators influence mean and semi-variance of revenues. For instance, heat stress exposure reduces expected milk revenues significantly. In the case of animal health-related indicators, our results show trade-offs between expected revenues and downside risks. Furthermore, variabilities in revenues from milk and animal sales are significantly interrelated. 1. Introduction The dairy sector is vitally important for agriculture, especially in Europe which is the largest milk producer worldwide (e.g. Bouamra-Mechemache, Jongeneel and Réquillart, 2008; Hirsch and Hartmann, 2014). Dairy producers face a number of risks, such as volatile quantities and qualities of outputs, institutional risks and fluctuating market prices (e.g. Chen, Roberts and Thraen, 2006; Wolf, Black and Hadrich, 2009; Valvekar et al., 2011; D’Antoni and Mishra, 2012; Henry et al., 2016). Production risks have been identified as crucial (Chen, Roberts and Thraen, 2006; Tveteras, Flaten, Lien and 2011; Berentsen, Kovacs and Van Asseldonk, 2012; Orea and Wall, 2012; El Benni and Finger, 2013) and are assumed to be driven by two main factors. Firstly, climatic variability and extreme climatic events affect the quantity and quality of animal products, such as milk and meat (e.g. Kadzere et al., 2002; Tubiello, Soussana and Howden, 2007; Key and Sneeringer, 2014). Secondly, animal health is essential for the production process and represents an important managerial component and source of income variability (e.g. Antle and Goodger, 1984; Lusk and Norwood, 2011; Hansson and Lagerkvist, 2014; Allendorf and Wettemann, 2015). Animal health can comprise various dimensions and is reflected in animal health-related indicators such as metabolic stress, the number of mastitis cases per cow or the frequency of animal losses (Oltenacu and Broom, 2010).1 Moreover, dairy production is characterised by a joint realisation of sales of milk and animals. In addition, revenues from animal sales are stochastic and contribute to adjustments of overall risks faced by the farm (e.g. Tveteras, Flaten and Lien, 2011). The identification of key risk determinants in dairy production and the quantification of their impacts, combined with a deeper understanding of farm-level responses to risks are of outmost importance when seeking to support farmers’ risk management strategies, develop improved risk management tools and better policies. We aim to identify determinants of downside risk exposure in dairy farms and quantify their effects. We provide the first analysis of risks in dairy production that covers a unique combination of foci on (i) downside risks, (ii) a holistic representation of revenues from milk and animal sales, (iii) climatic extremes and (iv) the role of animal health. This extends earlier research on risks in dairy production that has focused only on individual aspects (e.g. Tveteras, Flaten and Lien, 2011; Antle and Goodger, 1984; Key and Sneeringer, 2014). Our analysis tests the significance of different determinants of production risks in the dairy sector, quantifies marginal effects of various inputs on farm-level revenues and revenues variability and thus aids the development of better policies to overcome risks. Furthermore, we extend the current literature by identifying non-linearities and critical thresholds for risk exposure of dairy farms. To this end, we develop a multi-output stochastic production framework that is applied to a case study on dairy production in Germany, the largest European milk producer and processor. We use a rich panel dataset of 390 dairy farms over the time span from 2007 to 2014 that includes details on the economic performance of the farms, animal health indicators as well as production relevant indicators for weather extremes. Our econometric model accounts for the effects of various inputs and control variables on mean and semi-variance of revenues from milk and animal sales. Moreover, the joint production framework chosen in our analysis allows us to consider input and control variable effects on the semi-covariance between both outputs. The remainder of this paper is structured as follows. We start by developing the theoretical economic and econometric backgrounds. The econometric implementation and the dataset used are described in the next section. Subsequently, results are presented and discussed. The final section contains our concluding remarks. 2. Economic and econometric framework 2.1. Economic framework We use a stochastic production function framework to describe effects of different inputs on expected outputs as well as production risks (see Saastamoinen, 2015, for a recent survey). In line with Antle (1983), we assume that farmers maximise their utility with respect to a vector of inputs X taking into account moments (1,…, m) of different outputs produced (1,…, j) as follows: maxxE[U(π)]=h[μ11(X),μ21(X),…,μm1(X);…;μ1j(X),μ2j(X),…,μmj(X)] (1) where μ1j(X) represents the expected revenues of output j, and μk=E(Πj−μ1j)k,k=2,…,m denotes the mth moment of the distribution with Πj being the vector of realisations of revenues for output j. The analysis of risk in dairy production is often restricted to the variance of revenues (see Antle and Goodger, 1984, for an exception). The focus of this assumption is only valid if mean and variance are sufficient to describe the revenue distribution, i.e. no higher moments exist, and/or farmers have no preferences for higher moments. However, these assumptions are rarely fulfilled as agricultural returns are characterised by extreme loss events and farmers are often downside risk averse (e.g. Antle, 1983; Di Falco and Chavas, 2006; Koundouri et al., 2009). In fact, downside risk exposure can create liquidity problems for a dairy farm and potentially lead to bankruptcy (Hansson and Lagerkvist, 2014). Expanding the framework to higher moments such as skewness and kurtosis often faces an empirical challenge, namely that null hypotheses are not rejected (e.g. Kim et al., 2014).2 Therefore, we propose the use of a semi-variance approach (see also Miranda and Glauber, 1991; Vedenov and Barnett, 2004) to account for downside risk without expanding the number of equations to be estimated. Semi-variance only accounts for losses that are below a specific benchmark. Here we focus on revenue realisations below the expected value so that the semi-variance of output j can be defined as SVarj(X)=E{Πj(X)−E(Πj(X))}2∀Πj(X)<E(Πj(X)). This semi-variance equals the variance for symmetric distributions. In contrast, if the revenue distribution is skewed, semi-variance and variance differ (Estrada, 2004). If the distribution of revenues is negatively skewed, representing downside risks, the semi-variance is larger than the variance. Thus, the expected utility approximated with semi-variances is lower than for an approximation with variances. The focus on semi-variance thus allows the downside risk to be presented in a simple two-parametric framework (Estrada, 2007).3 In addition, semi-covariances represent the interrelation of downside risk exposure across different outputs. More specifically, we consider two outputs of dairy farms: milk and animal sales. Focus is usually placed on the variability of production quantities (e.g. Antle and Goodger, 1984). Our approach, with concentration on revenues, is an improvement on this for the following reasons. First, revenue accounts for the variability of both quantity and quality of production, as the quality is implicitly considered in output prices. Second, as animals are sold at various stages, i.e. ranging from calves and heifers through to dairy cows sold off when they no longer serve for milk production, a quantity-based comparison (e.g. based on kg or number of animals sold) is not meaningful. Third, revenues also implicitly include price variabilities. Thus, revenues also account for correlations between quantities and prices for both outputs, i.e. for the effects of natural hedge (e.g. Schmit, Boisvert and Tauer, 2001). Fourth, revenues reflect farmers’ goal functions better than production quantities. Hence, revenue variabilities allow an unbiased assessment of risks faced by farmers (e.g. El Benni, Finger and Meuwissen, 2016). Furthermore, as input costs are expected to be deterministic, we assume that the focus on the distribution of revenues suffices to infer on the variability of income. Finally, investigating the determinants of downside risk for milk and animal sales separately has two important advantages over an analysis using aggregated revenues. It allows us to identify potentially asymmetric effects of management variables and climatic shocks on different sources of income. Moreover, by exposing the interrelation between two major income sources, we are able to identify potential drivers of high-risk events, where losses in both outputs occur jointly. This provides a better overall view of farm-level risks and helps to identify farm-level mechanisms of risk management behaviour. Thus, our framework focusses on mean, semi-variance and semi-covariance of revenues from milk and animal sales (j = 1 and 2, respectively), so that equation (1) simplifies to maxxE[U(π)]=h[E(Π1(X)),SVar(Π1(X));E(Π2(X)),SVar(Π2(X))]. In our analysis, an input xl can decrease or increase the semi-variance, i.e. can be downside risk de- or increasing, or can have no effect on revenue semi-variance: ∂SVarj∂xl<=>0. Since milk production and animal sales are by nature closely linked, we assume inputs to be non-allocable (see also Tveteras, Flaten and Lien, 2011). Thus, input use not only influences the distribution of individual revenues but also the semi-covariance of revenues. With s1 and s2 representing the shares of milk and animal sales in total sales, mean and semi-variance of total revenues π arising from milk and sales of animals can be summarised as follows: E(π)=s1E(Π1(X))+s2E(Π2(X)) (2) for expected total revenues and SVar(π)=s12SVar(Π1(X))+s22SVar(Π2(X))+2s1s2SCov1,2(X) (3) for total semi-variance (e.g. Estrada, 2007). Note that we assume a (downside) risk averse farmer, so that the utility increases for higher levels of expected revenues E(π), but decreases for, ceteris paribus, higher levels of revenue semi-variance SVar(π). SCov1,2(X) is the semi-covariance between revenues from both outputs, defined as SCov1,2(X)=E[{Π1(X)−E(Π1(X))}·{Π2(X)−E(Π2(X))}]∀Πj(X)<E(Πj(X)). If revenue realisations below the expected revenue levels are not perfectly positively correlated, the overall risk is reduced due to diversification to two assets instead of one. Thus, a decrease in the semi-covariance indicates, ceteris paribus, a decrease in the overall risk faced by the farmer and thus a utility increase. We estimate marginal effects of inputs on mean and semi-variance of both outputs as well as on their semi-covariance. 2.2. Econometric framework A stochastic production function according to Just and Pope (1978) and Antle (1983) is used to estimate the effects of inputs and other factors on the mean, semi-variance and semi-covariance of revenue distribution. The relationships between inputs and expected revenues from the two outputs milk and animal sales are estimated as follows: Π1=f1(X)+e1 (4) Π2=f2(X)+e2 (5) where f1 and f2 are production functions to be estimated and represent μ11(X) and μ12(X), while e1 and e2 are error terms, which contain information on the riskiness of production and the effects of inputs on semi-variances and semi-covariance. We assume that E(e1)=0,E(e2)=0 as well as E[(e1−)2]=SVar(Π1(X)) and E[(e2−)2]=SVar(Π2(X)), where ei− represents negative outcomes of ei, i.e. realisations below expected levels. The effect of inputs on revenue semi-variances is estimated as follows: E[(e1−)2]=g1(X)+ε1 (6) E[(e2−)2]=g2(X)+ε2 (7) where g1 and g2 are semi-variance functions to be estimated that indicate the effects of inputs and other factors on semi-variances. Moreover, the semi-covariance between production of both outputs is empirically captured by SCov(e1−,e2−), which is used to estimate the effects of input use via the covariance function g3: SCov(e1−,e2−)=E[e1−⋅e2−]=g3(X)+ε3 (8) 2.3. Econometric implementation The production function forms most commonly used, such as the Cobb–Douglas, other CES functions or transcendental, are subjected to major limitations regarding the representation of production technologies (e.g. Driscoll, McGuirk and Alwang, 1992; Asche and Tveterås, 1999). Moreover, these production functions restrict marginal risk to the positive state and therefore do not allow for risk reducing input factors (Wan and Anderson, 1990). Therefore, more flexible functional forms, such as linear quadratic (LQ), generalised Leontief or translog are needed for the empirical estimation of the mean function. We follow Asche and Tveterås (1999) and employ a LQ functional form4 for the mean revenue function of output j that also controls for animal health, climatic variability, and milk quotas of each farm i in year t: Πijt=αj0+∑lαjlxlit+0.5∑l∑nαjlnxlitxnit+∑qαjqzqit+∑tαjtDt+μij+eijt (9) Πijt with j = 1, 2 indicates revenues from the two outputs milk and sales of animals, while xit is a vector of l,n = 1, …, 5 inputs. In addition to inputs, we control for the impact of animal health, climatic stress and milk quotas on mean output reflected by the variable set zit (with q = 1, …, 5; presented in more detail in the next section). Dt are time-specific dummy variables with t = 1, …, 8. Similarly, unobserved, time-invariant farm-specific effects μij which are treated as fixed effects, are added to the model using dummy variables (e.g. Baltagi and Blien, 1998; McArthur and McCord, 2017). α is the vector of the coefficients to be calculated. We assume that the error term eijt is distributed with E(eijt)=0, SVar(eijt−)=gj(xit;zit;Dt;εijt;β) and SCov(ei1t−;ei2t−)=g3(xit;zit;Dt;εit;γ). Thus, both semi-variances and semi-covariance are functions of inputs, control variables, exogenous shocks ( εijtandεit) as well as parameters to be estimated ( βandγ)5: SVar(eijt−)=βj0+∑lβjlxlit+0.5∑l∑nβjlnxlitxnit+∑qβjqzqit+∑tβjtDt+εijt (10) SCov(ei1t−;ei2t−)=γ0+∑lγlxlit+0.5∑l∑nγlnxlitxnit+∑qγqzqit+∑tγtDt+εit (11) We assume no correlation of unobserved output shocks across farms or over time, i.e. Cov(eijt;epjt)=0 for i≠p and Cov(eijt;eijs)=0 for t≠s. Elasticity measures for the mean, semi-variance and semi-covariance functions with respect to inputs can be derived as follows: MeanEjl=∂fj∂xlxlfjformeanoutput, (12) SVarEjl=∂gj∂xlxlgjforoutputsemi-variance, (13) SCovE12l=∂g3∂xlxlg3foroutputsemi−covariance. (14) Positive (negative) elasticities with respect to input l indicate that l increases (decreases) revenue, downside risk and the simultaneous occurrence of extreme risk events related to different outputs. Presumably, exogenous shocks to milk production are simultaneously shocks to animal production and sales and vice versa which implies that the error terms of the equations defined by (9) and (10) are correlated. Previous studies (e.g. Tveteras, Flaten, Lien, 2011) have, therefore, enhanced the estimation efficiency by estimating those equations as systems of seemingly unrelated regression equations (SURE). This accounts for potential correlation between the error terms of different outputs (Zellner, 1962). However, we consider the same inputs and control variables for revenues from milk and animal sales so that SURE regressions do not improve the statistical efficiency of estimated parameters (Zellner and Huang, 1962; Zellner, 1962, 1963). Other studies (e.g. Du et al., 2015) account for possible cross-moment correlations by estimating a joint system of mean and variance equations based on the GMM estimator. This is based on the fact that in the Just and Pope (1978) stochastic production function framework, production risk appears as heteroscedasticity, rendering the OLS estimator inefficient. However, Asche and Tveterås (1999) show that when using heteroscedasticity, robust standard errors separating the estimation of mean and variance (semi-variance) functions can be superior as it permits a more detailed specification based on less restrictive functional forms for individual equations. We, therefore, estimate the mean, semi-variance and semi-covariance equations defined by equations (9–11) separately. We use a two-stage least squares (2SLS) instrumental variable approach to produce consistent estimations and account for possible endogeneity problems caused by correlation of control variables in the set zit with the error terms eijt. 3. Data and background Our database consists of a panel of 390 dairy farms over the time span from 2007 to 2014. The farms are located in the German federal state North Rhine-Westphalia (see Figure A1 in the Appendix for a map of the location of farms). The Chamber of Agriculture of North Rhine-Westphalia provided the data based on farms receiving extension services (see Allendorf and Wettemann, 2015). This database contains both financial and biotechnological information for these farms as well as information on production and animal health. The information is available on the annual scale only. In a subsequent step, this dataset is matched with weather data (described below). The sample comprises farms with a homogenous milking technology. More specifically, all dairy farms utilise conventional, i.e. non-automated, milking systems. Moreover, farms use similar breeds, i.e. Holstein Friesian cattle (73 per cent), followed by Pezatta rosa cows (20 per cent) and crossbreeds (7 per cent). Farms self-select into the extension services feeding into the database used. Thus, this sample only represents specialised dairy farms and so the results cannot be upscaled to dairy production in North Rhine-Westphalia or Germany as a whole. Annual revenues (in EUR) from milk and sales of animals are taken directly from the income statements of the farms. The latter comprise all revenues from selling animals, starting from the sale of calves and heifers through to dairy cows that no longer serve for milk production. The database provided no information on other income sources. However, in the case of the farms included in our analysis, we assume that milk and sales of animals generate the bulk of the farms’ total revenues. In line with the existing literature in this field (Antle and Goodger, 1984; Kumbhakar, 1993; Key and Sneeringer, 2014; Orea and Wall 2012; Tveteras, Flaten and Lien, 2011), we focus on the following production factors in our empirical analysis: (i) land (in hectares, ha), (ii) labour (in hours, h), (iii) purchased concentrate feed (in EUR total), (iv) the total number of cattle and (v) costs for material, machinery and buildings (in EUR). Definitions and summary statistics of all variables are reported in Table 1. In addition, we consider time dummies to account for technological change and control for general price developments. We assume that all inputs contribute to higher levels of milk and animal sales. Anticipated effects of production factors on risks are ambiguous, as earlier studies present contrasting results (Antle and Goodger, 1984; Kumbhakar, 1993; Orea and Wall 2011; Tveteras, Flaten and Lien, 2011). However, these studies consistently show that a higher intensity of production, in our study expressed by larger expenditures for concentrate feed and a higher number of animals, increases the riskiness of production. Thus, we expect that larger and more intensive production that relies heavily on bought (concentrate) feed is characterised not only by higher average production but also by more vulnerable production systems. Finally, we control for the impact of farm-related milk quotas measured in (energy corrected) kilogram (kg). No prior expectations can be deduced from earlier literature regarding the effect of inputs on the variability of sales of animals. However, Tveteras, Flaten and Lien (2011) show that all inputs with the exception of labour increase the variance of meat production. Table 1. Descriptive statistics Variable Definition Mean SD Min Max 1 Milk Milk output (revenues in € EC) 308,834.20 194,977.90 43,948.00 2,576,725.00 2 Animal sales Animal sales (revenues in €) 31,231.01 21,627.04 3,258.01 355,383.91 3 Land Farm land (ha) 85.66 38.29 21.48 333.29 4 Labour Labour (hours) 4,076.61 1,732.63 1,371.22 20,318.00 5 Feed Purchased concentrate feed (€) 69,859.72 50.969.77 1,486.86 684,227.30 6 Number of cattle No. of cattle 202.87 101.50 40.21 1,138.90 7 Costs Costs for material, machinery, and buildings (€) 77,894.80 50,593.16 13,945.00 589,589.40 8 Somatic cell count Number of somatic cells (th) 201.84 53.51 16 487 9 Animal losses Number of animal losses (in %) 3.50 2.90 0 23.9 10 Dead births Number of dead births (in %) 5.48 4.24 0 38.57 11 THI load 75 Temperature and humidity index 75 57.21 30.37 0.59 202.12 12 Milk quota Milk quota EC (kg) 774,892.60 414,412.50 180,659.00 4,500,000.00 13 First calving age First calving age (month) 28.06 2.17 22.60 41.40 14 Veterinary expenditure Veterinary expenditure (€/cow) 120.27 51.20 11.36 383.96 Milk semi-variance 3.03e9 8.44e9 645.27 2.66e11 Meat semi-variance 1.06e8 2.44e8 3.36 4.08e9 Semi-covariance 4.30e8 1.03e9 30,547.17 2.19e10 Number of farms*** 390 Number of observations 3118 Variable Definition Mean SD Min Max 1 Milk Milk output (revenues in € EC) 308,834.20 194,977.90 43,948.00 2,576,725.00 2 Animal sales Animal sales (revenues in €) 31,231.01 21,627.04 3,258.01 355,383.91 3 Land Farm land (ha) 85.66 38.29 21.48 333.29 4 Labour Labour (hours) 4,076.61 1,732.63 1,371.22 20,318.00 5 Feed Purchased concentrate feed (€) 69,859.72 50.969.77 1,486.86 684,227.30 6 Number of cattle No. of cattle 202.87 101.50 40.21 1,138.90 7 Costs Costs for material, machinery, and buildings (€) 77,894.80 50,593.16 13,945.00 589,589.40 8 Somatic cell count Number of somatic cells (th) 201.84 53.51 16 487 9 Animal losses Number of animal losses (in %) 3.50 2.90 0 23.9 10 Dead births Number of dead births (in %) 5.48 4.24 0 38.57 11 THI load 75 Temperature and humidity index 75 57.21 30.37 0.59 202.12 12 Milk quota Milk quota EC (kg) 774,892.60 414,412.50 180,659.00 4,500,000.00 13 First calving age First calving age (month) 28.06 2.17 22.60 41.40 14 Veterinary expenditure Veterinary expenditure (€/cow) 120.27 51.20 11.36 383.96 Milk semi-variance 3.03e9 8.44e9 645.27 2.66e11 Meat semi-variance 1.06e8 2.44e8 3.36 4.08e9 Semi-covariance 4.30e8 1.03e9 30,547.17 2.19e10 Number of farms*** 390 Number of observations 3118 All monetary values are adjusted for the value-added tax. Based on the requirements for weather stations presented above, the THI was calculated based on an overall number of 15 weather stations for the 390 farms. The number of cattle is measured as livestock units where calves and young animals (<1 year) equal 0.3 units, <2 years 0.7 units and remaining animals 1 unit. Table 1. Descriptive statistics Variable Definition Mean SD Min Max 1 Milk Milk output (revenues in € EC) 308,834.20 194,977.90 43,948.00 2,576,725.00 2 Animal sales Animal sales (revenues in €) 31,231.01 21,627.04 3,258.01 355,383.91 3 Land Farm land (ha) 85.66 38.29 21.48 333.29 4 Labour Labour (hours) 4,076.61 1,732.63 1,371.22 20,318.00 5 Feed Purchased concentrate feed (€) 69,859.72 50.969.77 1,486.86 684,227.30 6 Number of cattle No. of cattle 202.87 101.50 40.21 1,138.90 7 Costs Costs for material, machinery, and buildings (€) 77,894.80 50,593.16 13,945.00 589,589.40 8 Somatic cell count Number of somatic cells (th) 201.84 53.51 16 487 9 Animal losses Number of animal losses (in %) 3.50 2.90 0 23.9 10 Dead births Number of dead births (in %) 5.48 4.24 0 38.57 11 THI load 75 Temperature and humidity index 75 57.21 30.37 0.59 202.12 12 Milk quota Milk quota EC (kg) 774,892.60 414,412.50 180,659.00 4,500,000.00 13 First calving age First calving age (month) 28.06 2.17 22.60 41.40 14 Veterinary expenditure Veterinary expenditure (€/cow) 120.27 51.20 11.36 383.96 Milk semi-variance 3.03e9 8.44e9 645.27 2.66e11 Meat semi-variance 1.06e8 2.44e8 3.36 4.08e9 Semi-covariance 4.30e8 1.03e9 30,547.17 2.19e10 Number of farms*** 390 Number of observations 3118 Variable Definition Mean SD Min Max 1 Milk Milk output (revenues in € EC) 308,834.20 194,977.90 43,948.00 2,576,725.00 2 Animal sales Animal sales (revenues in €) 31,231.01 21,627.04 3,258.01 355,383.91 3 Land Farm land (ha) 85.66 38.29 21.48 333.29 4 Labour Labour (hours) 4,076.61 1,732.63 1,371.22 20,318.00 5 Feed Purchased concentrate feed (€) 69,859.72 50.969.77 1,486.86 684,227.30 6 Number of cattle No. of cattle 202.87 101.50 40.21 1,138.90 7 Costs Costs for material, machinery, and buildings (€) 77,894.80 50,593.16 13,945.00 589,589.40 8 Somatic cell count Number of somatic cells (th) 201.84 53.51 16 487 9 Animal losses Number of animal losses (in %) 3.50 2.90 0 23.9 10 Dead births Number of dead births (in %) 5.48 4.24 0 38.57 11 THI load 75 Temperature and humidity index 75 57.21 30.37 0.59 202.12 12 Milk quota Milk quota EC (kg) 774,892.60 414,412.50 180,659.00 4,500,000.00 13 First calving age First calving age (month) 28.06 2.17 22.60 41.40 14 Veterinary expenditure Veterinary expenditure (€/cow) 120.27 51.20 11.36 383.96 Milk semi-variance 3.03e9 8.44e9 645.27 2.66e11 Meat semi-variance 1.06e8 2.44e8 3.36 4.08e9 Semi-covariance 4.30e8 1.03e9 30,547.17 2.19e10 Number of farms*** 390 Number of observations 3118 All monetary values are adjusted for the value-added tax. Based on the requirements for weather stations presented above, the THI was calculated based on an overall number of 15 weather stations for the 390 farms. The number of cattle is measured as livestock units where calves and young animals (<1 year) equal 0.3 units, <2 years 0.7 units and remaining animals 1 unit. In addition to the standard set of input variables described above, we also explicitly account for animal health and climate stress. Animal health cannot be measured directly, so we can only observe outcomes that arise from the animals’ health status. For our analysis, these comprise (i) somatic cell count, (ii) the relative number of dead births (n.d.b.) and (iii) the relative number of animal losses (n.a.l.). Somatic cell count (s.c.c.) is a proxy for mastitis problems, one of the major animal health threats for dairy farms in Germany (Müller and Sauerwein, 2010). Furthermore, perinatal and postnatal mortality (reflected by n.b.d. and n.a.l.) of dairy cattle represents a source of severe economic losses in European dairy production (e.g. Gundelach et al., 2009; Raboisson et al., 2013). We face potential endogeneity issues relating to these animal health variables, as they might be influenced by undetected management factors or other environmental factors (see e.g. Harmon, 1994, for an overview). While time-invariant components of these factors (e.g. related to animal housing) are captured by farm-specific fixed effects, the correlation with time variant factors (e.g. feeding and milking management) can cause endogeneity problems. We use a 2SLS instrumental variable approach to cope with this. Lagged variables of s.c.c., n.a.l. and n.d.b. are considered as instruments. Moreover, we include lagged observations of key management variables that are expected to influence animal health as additional instruments. More specifically, we include lagged veterinary expenditure (in EUR per cow) and the first calving age (herd average) because these are decisive for animal health and dairy herd management (e.g. Ettema and Santos, 2004; Haworth et al. 2008). Veterinary expenditure might reflect preventive or curative measures to improve animal health (Antle and Goodger, 1984). Regarding first calving, Ettema and Santos (2004) show that if this occurs at an early age it is often associated with a higher incidence of stillbirths, as well as affecting other animal health-related outcomes such as mastitis and in the end reduces milk yields and milk components. Animal health problems as well as the possible link between the first calving age and other performance relevant factors, such as body weight (Ettema and Santos, 2004), are expected to influence milk performance. This encourages its use as an instrument instead of including it the main equation. Moreover, Haworth et al. (2008) find that early first calving leads to an increase in health problems and a decline in the cow’s life expectancy. The first calving age and veterinary expenditure are not included in the second stage regression analysis but serve only as instruments. We expect that low animal health status, as indicated by high levels of s.c.c., n.a.l. and n.d.b., respectively, increases the downside risk related to milk sales (see e.g. Antle and Goodger, 1984; Harmon, 1994). This is due to the fact that a higher probability of perinatal and postnatal mortalities plus situations where milk cannot be marketed (e.g. in cases of mastitis) imply more frequent deviations from the expected milk revenues. In this context, farmers also state that maintaining animal health can represent an important risk management strategy (e.g. Musser and Patrick, 2002). The expected effects of animal health on the anticipated milk sales are ambiguous. Animal health problems reduce potential sales of milk. However, there might also be trade-offs between animal health and expected milk sales. For example, although later first calving might imply better animal health it also lengthens the heifer’s non-productive time and thus increases total output (e.g. Ettema and Santos, 2004; Hare, Norman and Wright, 2006; Lawson et al., 2004). In fact, in various countries, there is a growing trend towards an earlier first calving age, which imply lower animal health but higher revenues (see e.g. Hare, Norman and Wright, 2006). Anticipated effects of s.c.c., n.a.l. and n.d.b. on sales of animals are ambiguous. We expect a negative effect since elevated disease rates in the population may mean that cows scheduled for sale have to be kept in order to maintain high-milk production levels. However, high-disease rates in the population leads to a larger number of non-productive cows thus, depending on the infection frequency, it might also increase sales. Moreover, a growing number of mortality events are expected to increase volatility of the revenue streams from animal sales. Like Key and Sneeringer (2014,) we expect heat waves to be one of the most serious extreme climatic events for dairy producers, affecting both milk production and animal sales. Since both temperature and humidity must be considered jointly to depict perceived heat stress, we focus on temperature humidity indices (THI) in our analysis. We expect climate stress to reduce expected production levels and increase (downside) risks. In line with Bohmanova, Misztal and Cole (2007), we chose a THI index that is especially suited to our case study region (with low levels of humidity), i.e. with a particular emphasis on ambient temperature.6 We use daily maximum and minimum temperatures as well as relative humidity values to calculate daily THImax THImin values. Like Bohmanova, Misztal and Cole (2007), we assume that the daily THI profile follows a sine curve between these two values and thus calculate the daily THIload as the area between the THI sine curve and the THIThreshold above which temperature stress is assumed to occur. The final THI value used in our analysis is an annual aggregate of daily THIload values. The THI threshold values indicated in the literature vary between 70 and 78 (Igono, Bjotvedt and Sanford-Crane, 1992; St-Pierre, Cobanov and Schnitkey, 2003; Key and Sneeringer, 2014; Dash et al., 2016). The results presented here are based on the threshold value of 75 but we also conducted sensitivity analyses with threshold values equal to 70 and 80 and obtained similar effects.7 Farm-level data were matched with local weather data. For each farm, we used the closest weather station that provides a complete time series of daily temperature and relative humidity information over the entire study period (Hill and Wall, 2015; Wetterdienst, 2016). The resulting THI values show a large heterogeneity over space and time (see Figure 1 and Figure A2 in the Appendix, respectively). More specifically, we find that the THI load varies from almost 0 to over 200 in our sample. Note that structural differences with respect to the climatic risk exposure of the farms are captured in the farm-specific fixed effects of our analysis. Furthermore, we are aware that heat stress also potentially affects the animal health-related outcomes, such as animal losses, considered in our analysis (see e.g. Raboisson et al. 2013; Stull et al., 2008). However, the 2SLS approach used here does capture parts of the heat stress implications in the animal health proxies. Fig. 1. View largeDownload slide THI load for the year 2010. Points represent the location of each farm and the colour indicates the THI load. See Figure A1 in the Appendix for a presentation of the farms’ location in Germany as a whole. Fig. 1. View largeDownload slide THI load for the year 2010. Points represent the location of each farm and the colour indicates the THI load. See Figure A1 in the Appendix for a presentation of the farms’ location in Germany as a whole. Table 1 presents summary statistics of the variables8 considered. Although our analysis is based on a set of farms with similar production techniques in North Rhine-Westphalia, we find that the factor endowment with land, labour, cattle and milk quotas differs largely across these farms. On an average, the farms have about 86 ha of land under production and over 200 cattle. Moreover, we find animal sales to be important for our sample farms as they are naturally linked to dairy production and contribute almost 10 per cent of the total revenues. In the Appendix, we present a correlation matrix of all variables (Table A1). 4. Results and discussion Table 2 presents elasticity and coefficient estimates for inputs9 and control variables,10 respectively. Results for the mean functions specified by equation (9) reveal that most inputs have a positive significant effect on the expected milk sales. In contrast, the production factor land has no significant effect on milk sales, indicating the relevance of the substitutability of the production factor land and concentrate feed in the production systems investigated here. In contrast, only a positive significant effect of concentrate feed is found for animal sales. The THI index has a significant negative effect on the expected levels of milk revenues. Thus, heat stress significantly affects dairy production, even in the highly developed, specialised dairy production in North Rhine-Westphalia. This highlights the need to develop adaptation strategies to cope with the effects of increasing climatic variability and more pronounced climatic extremes (e.g. Key and Sneeringer, 2014). Figure 2 further illustrates the economic relevance of these effects. We used a simulation framework where the coefficient estimates of the impact of THI load 75 on milk revenues, as displayed in Table 2, have been multiplied by the historical THI exposure of each farm and year.11 Shaded areas stretch from minimum and maximum values observed at individual farms, whereas the solid line shows the estimated average effect across farms. This figure reveals the high economic impact of the THI, with average heat stress induced losses in milk revenues amounting to about EUR 10,000 per year, while it can exceed EUR 25,000 per year for individual farms. The simulations in Figure 2 further highlight the substantial degree of heterogeneity of heat stress induced effects across time and space. Table 2. Input elasticity estimates and regression coefficients for THI, milk quota and animal health factors Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.010 0.773** 0.097 −0.370 0.542* (0.037) (0.331) (0.129) (0.270) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.333*** 0.871 0.338*** 0.283 0.958* (0.034) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) (0.509) (0.661) Costs 0.119*** 0.472 -0.092 0.127 0.155 (0.024) (0.576) (0.071) (0.879) (0.460) Regression coefficients THI load 75 −167.361*** 2.84e6 10.251 3.88e5* 6.86e5 (51.782) (5.55e6) (16.577) (2.10e5) (7.76e5) Somatic cell count −228.150** −5.92e6*** 4.181 −1.57e5* −4.18e5 (98.711) (2.22e6) (31.600) (9.51e4) (3.51e5) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (1.83e6) (7.81e6) Dead births 250.048 6.08e7** −433.959 −9.85e5 5.54e6 (1,893.67) (2.66e7) (563.841) (1.03e6) (4.45e6) Milk quota 0.103*** 1,553.617 0.001 83.804 234.581 (0.027) (1,443.749) (0.005) (63.736) (193.063) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 p-value 0.000 0.000 Sargan χ2 1.473 0.064 p-value 0.479 0.969 n 2,630 1,706 2,630 1,573 1,001 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Arellano and Bond z = 1.03 z = 0.42 AR(1) p = 0.305 p = 0.677 Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.010 0.773** 0.097 −0.370 0.542* (0.037) (0.331) (0.129) (0.270) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.333*** 0.871 0.338*** 0.283 0.958* (0.034) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) (0.509) (0.661) Costs 0.119*** 0.472 -0.092 0.127 0.155 (0.024) (0.576) (0.071) (0.879) (0.460) Regression coefficients THI load 75 −167.361*** 2.84e6 10.251 3.88e5* 6.86e5 (51.782) (5.55e6) (16.577) (2.10e5) (7.76e5) Somatic cell count −228.150** −5.92e6*** 4.181 −1.57e5* −4.18e5 (98.711) (2.22e6) (31.600) (9.51e4) (3.51e5) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (1.83e6) (7.81e6) Dead births 250.048 6.08e7** −433.959 −9.85e5 5.54e6 (1,893.67) (2.66e7) (563.841) (1.03e6) (4.45e6) Milk quota 0.103*** 1,553.617 0.001 83.804 234.581 (0.027) (1,443.749) (0.005) (63.736) (193.063) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 p-value 0.000 0.000 Sargan χ2 1.473 0.064 p-value 0.479 0.969 n 2,630 1,706 2,630 1,573 1,001 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Arellano and Bond z = 1.03 z = 0.42 AR(1) p = 0.305 p = 0.677 Notes: Values for inputs (land, labour, feed, number of cattle and costs) are output elasticities w.r.t. those inputs; values for somatic cell count, calving age, THI load 75, and milk quota are regression coefficients. Heteroskedasticity robust standard errors in parentheses. *, ** and *** indicate significance at the 10, 5 and 1 per cent level, respectively. Table 2. Input elasticity estimates and regression coefficients for THI, milk quota and animal health factors Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.010 0.773** 0.097 −0.370 0.542* (0.037) (0.331) (0.129) (0.270) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.333*** 0.871 0.338*** 0.283 0.958* (0.034) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) (0.509) (0.661) Costs 0.119*** 0.472 -0.092 0.127 0.155 (0.024) (0.576) (0.071) (0.879) (0.460) Regression coefficients THI load 75 −167.361*** 2.84e6 10.251 3.88e5* 6.86e5 (51.782) (5.55e6) (16.577) (2.10e5) (7.76e5) Somatic cell count −228.150** −5.92e6*** 4.181 −1.57e5* −4.18e5 (98.711) (2.22e6) (31.600) (9.51e4) (3.51e5) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (1.83e6) (7.81e6) Dead births 250.048 6.08e7** −433.959 −9.85e5 5.54e6 (1,893.67) (2.66e7) (563.841) (1.03e6) (4.45e6) Milk quota 0.103*** 1,553.617 0.001 83.804 234.581 (0.027) (1,443.749) (0.005) (63.736) (193.063) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 p-value 0.000 0.000 Sargan χ2 1.473 0.064 p-value 0.479 0.969 n 2,630 1,706 2,630 1,573 1,001 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Arellano and Bond z = 1.03 z = 0.42 AR(1) p = 0.305 p = 0.677 Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.010 0.773** 0.097 −0.370 0.542* (0.037) (0.331) (0.129) (0.270) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.333*** 0.871 0.338*** 0.283 0.958* (0.034) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) (0.509) (0.661) Costs 0.119*** 0.472 -0.092 0.127 0.155 (0.024) (0.576) (0.071) (0.879) (0.460) Regression coefficients THI load 75 −167.361*** 2.84e6 10.251 3.88e5* 6.86e5 (51.782) (5.55e6) (16.577) (2.10e5) (7.76e5) Somatic cell count −228.150** −5.92e6*** 4.181 −1.57e5* −4.18e5 (98.711) (2.22e6) (31.600) (9.51e4) (3.51e5) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (1.83e6) (7.81e6) Dead births 250.048 6.08e7** −433.959 −9.85e5 5.54e6 (1,893.67) (2.66e7) (563.841) (1.03e6) (4.45e6) Milk quota 0.103*** 1,553.617 0.001 83.804 234.581 (0.027) (1,443.749) (0.005) (63.736) (193.063) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 p-value 0.000 0.000 Sargan χ2 1.473 0.064 p-value 0.479 0.969 n 2,630 1,706 2,630 1,573 1,001 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Arellano and Bond z = 1.03 z = 0.42 AR(1) p = 0.305 p = 0.677 Notes: Values for inputs (land, labour, feed, number of cattle and costs) are output elasticities w.r.t. those inputs; values for somatic cell count, calving age, THI load 75, and milk quota are regression coefficients. Heteroskedasticity robust standard errors in parentheses. *, ** and *** indicate significance at the 10, 5 and 1 per cent level, respectively. Fig. 2. View largeDownload slide Historical simulation of impact of THI load 75 on milk revenues. Note that (i) the impact of THI load 75 on milk revenues displayed here is based on the estimated relationship between milk revenues and the historical THI exposure, (ii) shaded areas indicate minimum and maximum impacts and (ii) the solid line indicates the average effect of THI on milk revenues. Fig. 2. View largeDownload slide Historical simulation of impact of THI load 75 on milk revenues. Note that (i) the impact of THI load 75 on milk revenues displayed here is based on the estimated relationship between milk revenues and the historical THI exposure, (ii) shaded areas indicate minimum and maximum impacts and (ii) the solid line indicates the average effect of THI on milk revenues. In addition, milk quotas are found to significantly increase expected levels of dairy revenues. Note, however, that quota levels are not strictly binding and farms in our sample over- and underuse their quota levels significantly. Thus, the quota level is not the only predictor for milk revenues. On an average, the quota use is at a level of 108 per cent, with a high level of heterogeneity across farms (see also Table 1).12 Animal health variables reflect a significant negative effect of the s.c.c. on expected milk revenues. In contrast, higher relative animal losses are associated with an increase of the expected milk revenues. This finding highlights the potential trade-off in the interrelation between animal health and revenues. For example, this might reflect that first calving at a later age might improve animal health and reduce animal losses but also decreases expected revenues due to forgone lactating periods. We find animal losses only have a significant positive effect with regard to expected animal sales. In general, lower animal health might be correlated with a higher turnover of animals, leading to more frequent sales. Both mean functions were estimated using a 2SLS instrumental variable approach to account for the possible endogeneity of the variables ssc, n.a.l. and n.d.b., whereby the insignificant Sargan test statistics indicate that the over-identifying restrictions are not rejected.13 Furthermore, we assess the relevance of the instruments included based on the minimum eigenvalue statistic by Cragg and Donald (1993) which constitutes the adequate measure if the number of endogenous regressors is larger than one. The null hypothesis of weak instruments is rejected14 for both the mean milk and animal sales functions. This implies that lagged values of s.c.c., n.a.l., n.d.b. as well as the lagged values of the first calving age and veterinary expenditure constitute valid and relevant instruments. Note that the inclusion of lagged explanatory variables, or the use of these variables as instruments in a 2SLS framework, only purges estimates of endogeneity if (i) autocorrelation among the residuals is not present (e.g. Ansell, 2008; Bellemare, Masaki and Pepinsky, 2017; Betz, Cook and Hollenbach, 2018) and (ii) if the lagged values are themselves not present as explanatory factors in the main equation (e.g. Reed, 2015). We, therefore, apply Arellano and Bond’s (1991) AR test which is particularly suited to assess the presence of autocorrelation in the residuals of 2SLS estimations. The bottom line of Table 2 indicates that the null hypothesis of no autocorrelation is not rejected for either of the mean functions relating to both the mean milk and the mean meat estimation. This confirms the appropriateness of using lags as instruments. Moreover, the argumentation of causality in our instrumentation strategy as presented above encourages the use of these variables as instruments instead of their inclusion in the main equation. Estimates for the semi-variance functions specified by equation (10) are presented in the third and fifth columns of Table 2. Moreover, the effects of selected variables (number of cattle, labour and concentrate feed) on expected revenues (absolute effects) and semi-variance (marginal effects) are illustrated in Figure 3 (the graphs for all variables are given in the Appendix). Figure 3 thus reveals the heterogeneities in the effects on both expected revenues and semi-variance across realisations of the respective variables in our sample (represented as histograms). Fig. 3 View largeDownload slide Impact of inputs on expected revenues (absolute effects) and semi-variance (marginal effects) of milk production and animal sales. Note that (i) black lines represent effects on expected revenues and grey lines represent effects on semi-variances and insignificant effects are displayed as dashed lines, (ii) histograms solely refer to the respective input and not to the ordinate axis, (iii) displayed input quantity ranges are based on the average value ± the interquartile range multiplied by 1.5 (boxplot whiskers) and (iv) values of all other variables are held constant at the average. Fig. 3 View largeDownload slide Impact of inputs on expected revenues (absolute effects) and semi-variance (marginal effects) of milk production and animal sales. Note that (i) black lines represent effects on expected revenues and grey lines represent effects on semi-variances and insignificant effects are displayed as dashed lines, (ii) histograms solely refer to the respective input and not to the ordinate axis, (iii) displayed input quantity ranges are based on the average value ± the interquartile range multiplied by 1.5 (boxplot whiskers) and (iv) values of all other variables are held constant at the average. Our results show that land significantly increases the semi-variance of milk revenues, i.e. (downside) risk increasing, while the coefficients of other inputs such as labour and concentrate feed are positive as indicated in earlier studies (e.g. Tveteras, Flaten and Lien, 2011; Kumbhakar, 1993; Orea and Wall 2011), but these coefficients are not significant in our analysis. The impact of the number of cattle on downside risks is expected to have two relevant effects. Firstly, in the case of idiosyncratic risks affecting only individual animals, a larger herd size implies that aggregating over a larger number of individual production units leads to a reduction of total variability (see e.g. Marra and Schurle, 1994, for examples of crop production). Secondly, in the case of systemic risks affecting all the animals in the entire herd equally, larger herd sizes may imply an increasing risk. Our results show that – on average – the former effect dominates for milk revenues, i.e. a larger number of cattles reduce risk. However, the effects of herd size on downside risks are found to be non-uniform across all farms. A closer look at the impact of the number of cattle reveals that the respective effect on milk revenues varies across herd sizes (holding all other variables at their respective average value; see the third column of Figure 3). More specifically, with increasing herd sizes, the risk reducing effect vanishes. We find the number of cattle increases the semi-variance of animal sales, confirming the results of Tveteras, Flaten and Lien (2011). Thus, the total effect of the herd size on risk exposure at the farm-level remains ambiguous as milk revenue variability decreases and the variability of animal sales increases. Again, this effect is not uniform across herd sizes. Figure 3 shows that the number of cattle decreases semi-variance for herd sizes of less than about 120, but increases semi-variance for larger herds. Furthermore, we find that labour input decreases downside risks in animal sales revenues, which is in line with the findings of Tveteras, Flaten and Lien (2011) (for meat sales). In addition, we find clear indications that animal health affects semi-variances of milk and animal sales. More specifically, we find a significant positive effect of the share of animal losses and dead births on the semi-variance of milk revenues, which indicates that lower animal health status leads to higher downside risk exposure. In contrast, we find the semi-variance of milk sales decreases with increasing s.c.c.. Regarding the semi-variance of animal sales, we find a downside risk increasing effect of the share of animal losses, while the s.c.c. reduces the semi-variance of animal sales. In the case of heat stress, the THI index was found to have no significant effect on the semi-variance of milk revenues, even though it has a significant impact on production levels. This result might be due to the fact that there were very few extreme climatic events during the sample period in our analysis. However, a higher THI index is found to increase the semi-variance of animal sales. This result could indicate that in heat stress situations, animal sales are possibly postponed to maintain milk production. Milk quotas do not influence the degree of extreme risks related to both milk and animal sales. Finally, the semi-covariance function (equation (11)) reveals that the number of animal losses, farm land and concentrate feed expenditure increase the semi-covariance, i.e. further increase the downside risk exposure of dairy farms as the probability of concurrent occurrence of below-average outcomes in milk and animal sales rises. 5. Conclusion Our analysis for dairy farms in North Rhine-Westphalia (Germany) reveals significant effects of production inputs on expected revenues from both milk and animal sales. The effects of inputs on semi-variances remain inconclusive but reveal that not all inputs affect dairy farms’ risk uniformly. For instance, different input variables have been identified to influence downside risk exposure for milk and animal sales. Moreover, we find that herd size (on average) decreases the downside risks in milk revenues, but increases downside risks in animal sales. Thus, the risk effects of inputs or control variables can be outweighed or amplified when analysing them in a joint system. Furthermore, we find that farm land and expenditure for concentrate feed increase the semi-covariance, i.e. to ceteris paribus increase the likelihood of a joint occurrence of below-average outcomes in milk and animal sales. Therefore, our analysis highlights the relevance of a holistic farm-level risk assessment that also accounts for non-milk outputs that naturally occur at dairy farms. Furthermore, the findings on the semi-covariance partly support the hypothesis that intensive production methods based strongly on concentrate feed are more vulnerable. We find that animal health is an integral component of both expected revenues and production risks. More specifically, a higher somatic cell count results in lower milk revenues. In contrast, a higher number of animal losses is associated with higher dairy and animal sales but also increases the semi-variance of the revenues generated by both outputs. This highlights the potential trade-offs in animal health between expected revenues and downside risk exposure. Thus, risk averse decision makers will choose management measures (e.g. later first calving ages), that reduce animal losses and lead to lower downside risk exposure but, at the same time, imply opportunity costs in terms of forgone revenues. This finding also outlines potential critical effects of the subsidisation of risk management tools such as the income stabilisation tool (e.g. El Benni, Finger and Meuwissen, 2016) currently under discussion. More specifically, provision against income variability might encourage more risky production decisions, implying that lower levels of animal health are the best choice. Finally, we find that heat stress has a significant negative effect on milk revenues. Even though the farms studied here operate under highly professional conditions and use state of the art technologies, extreme climatic events have marked economic effects on milk revenues. The economic relevance of these heat stress events is expected to increase even further due to climate change and must therefore be accounted for in long-term investment decisions. Risk management instruments tailored to heat stress, e.g. using index insurance solutions, can be developed based on the marginal effects of heat stress on dairy farm revenues indicated here (e.g. Deng et al., 2007; Vermeulen et al., 2012). The role of risk preferences across farms must be studied more closely. To this end, econometric analysis should be combined with experimental approaches to elicit risk preferences (e.g. Vollmer, Hermann and Mußhoff, 2017). Moreover, future analysis also should consider adjustments at the household level involving the use of resources (e.g. labour and land) off the farm (e.g. De Mey et al., 2016). Supplementary data Supplementary data are available at European Review of Agricultural Economics online. Acknowledgements We would like to thank the Chamber of Agriculture of North Rhine-Westphalia for providing access to the farm-level data and the Deutscher Wetterdienst for access to the weather data. Furthermore, we thank three anonymous reviewers for constructive comments on an earlier draft of this paper. Footnotes 1 More generally, Curtis (2007) proposes a performance-oriented perspective on the animal state of being, e.g. by addressing a gap between the potential and the observed production and reproductive performance. 2 Similarly, in our analysis, the consideration of skewness and co-skewness did not reveal any conclusive empirical findings. 3 In general, the focus on lower partial moments as risk measure is consistent with maximisation of expected utility (Jarrow and Zhao, 2006; Gatzert and Kling, 2007) and provides a more coherent representation of downside risks (e.g. Antle, 2010). 4 More specifically, Asche and Tveterås (1999) compare the LQ it to a generalised Leontief function, which is also employed by Tveteras, Flaten and Lien (2011), and show that the specification does not matter. We have chosen the LQ over other specifications due to the more straightforward implementation w.r.t. the derivation of margins and their significance levels and better fit (e.g. expressed by AIC values). 5 While farm-specific fixed effects are added to the mean function (see equation (9)) to control for unobserved differences in technologies used, the subsequent estimation steps in equations (10g) and (11) are based on residuals derived from this first estimation step. Thus, we assume no further unobserved differences across farms with respect to risk profiles and do not include farm-specific effects in the estimation of semi-variance and semi-covariance functions. 6 More specifically, based on Bohmanova, Misztal and Cole (2007), we calculate the THI as: THI = (1.8Tdb + 32) − (0.55 − 0.0055RH)(1.8Tdb − 26) where, Tdb and RH denote the dry bulb temperature (in degrees Celsius) and the relative humidity (in per cent), respectively. 7 The full results of the sensitivity analysis with THI thresholds of 70 and 80 are available upon request. Note that the threshold of 80 only results in a limited number of heat stress observations. 8 Note that we removed two observations using multidimensional outlier detection based on the BACON algorithm proposed by Billor, Hadi and Velleman (2000). The BACON algorithm identifies outliers in a multidimensional framework based on Mahalanobis distances (Weber, 2010). The two not considered observations were characterised by an implausibly large animal density per hectare, especially compared to pre- and succeeding observations of the same farms and thus probably represent errors in the data collection process. 9 See Table A3 in the Appendix for coefficients of the input interaction terms. 10 As regard model diagnostics, Wald tests (for mean functions estimated with 2SLS) and F-tests (for semi-variance and semi-covariance functions estimated with OLS) reveal the overall significance of all models. Variance inflation factors reveal no indication for multicollinearity. Furthermore, the qualitative interpretation of results does not change if individual potentially correlated variables are removed. 11 Note that the approach chosen here probably underestimates the effects of heat stress on revenues because our econometric model also accounts for year dummies. Therefore, systemic events such as a heat waves are partly captured in the year dummy (that also includes other effects such as price shocks) and the THI effect that is presented here. 12 A super levy must be paid if quota levels are exceeded (see e.g. Francksen, Hagemann, Latacz‐Lohmann, 2012). 13 In both cases, Sargan tests of overidentifying restrictions are highly insignificant indicating that the selected instruments are orthogonal to the errors and hence valid. 14 First-stage regression results of the 2SLS mean functions are reported in the Table A2 in the Appendix. References Allendorf , J. and Wettemann , P. ( 2015 ). Does animal welfare influence dairy farm efficiency? A two-stage approach . Journal of Dairy Science 98 ( 11 ): 7730 – 7740 . Google Scholar CrossRef Search ADS PubMed Ansell , B. W. ( 2008 ). Traders, teachers, and tyrants: democracy, globalization, and public investment in education . International Organization 62 : 289 – 322 . Google Scholar CrossRef Search ADS Antle , J. M. ( 1983 ). Testing the stochastic structure of production: a flexible moment-based approach . Journal of Business & Economic Statistics 1 ( 3 ): 192 – 201 . Antle , J. M. ( 2010 ). Asymmetry, partial moments and production risk . American Journal of Agricultural Economics 92 ( 5 ): 1294 – 1309 . Google Scholar CrossRef Search ADS Antle , J. M. and Goodger , W. J. ( 1984 ). Measuring stochastic technology: the case of Tulare milk production . American Journal of Agricultural Economics 66 ( 3 ): 342 – 350 . Google Scholar CrossRef Search ADS Arellano , M. and Bond , S. ( 1991 ). Some tests of specification for panel data: Monte Carlo evidence and an application to employment equations . The Review of Economic Studies 58 : 277 – 297 . Google Scholar CrossRef Search ADS Asche , F. and Tveterås , R. ( 1999 ). Modeling production risk with a two-step procedure . Journal of Agricultural and Resource Economics 24 ( 2 ): 424 – 439 . Baltagi , B. H. and Blien , U. ( 1998 ). The German wage curve: evidence from the IAB employment sample . Economic Letters 61 : 135 – 142 . Google Scholar CrossRef Search ADS Bellemare , M. F. , Masaki , T. and Pepinsky , T. B. ( 2017 ). Lagged explanatory variables and the estimation of causal effect . The Journal of Politics 79 ( 3 ): 949 – 963 . Google Scholar CrossRef Search ADS Berentsen , P. B. M. , Kovacs , K. and Van Asseldonk , M. A. P. M. ( 2012 ). Comparing risk in conventional and organic dairy farming in the Netherlands: an empirical analysis . Journal of Dairy Science 95 ( 7 ): 3803 – 3811 . Google Scholar CrossRef Search ADS PubMed Betz , T. , Cook , S. J. and Hollenbach , F. M. ( 2018 ). On the use and abuse of spatial instruments . Political Analysis (forthcoming). Billor , N. , Hadi , A. S. and Velleman , P.F. ( 2000 ). Computational Statistics & Data Analysis , 34 , BACON : Blocked adaptive computationally efficient outlier nominators , 279 – 298 . Bohmanova , J. , Misztal , I. and Cole , J. B. ( 2007 ). Temperature–humidity indices as indicators of milk production losses due to heat stress . Journal of Dairy Science 90 ( 4 ): 1947 – 1956 . Google Scholar CrossRef Search ADS PubMed Bouamra-Mechemache , Z. , Jongeneel , R. and Réquillart , V. ( 2008 ). Impact of a gradual increase in milk quotas on the EU dairy sector . European Review of Agricultural Economics 4 : 461 – 491 . Google Scholar CrossRef Search ADS Chen , G. , Roberts , M. C. and Thraen , C. S. ( 2006 ). Managing dairy profit risk using weather derivatives . Journal of Agricultural and Resource Economics 31 ( 3 ): 653 – 666 . Cragg , J. G. and Donald , S. G. ( 1993 ). Testing identifiability and specification in instrumental variable models . Econometric Theory 9 : 222 – 240 . Google Scholar CrossRef Search ADS Curtis , S. E. ( 2007 ). COMMENTARY: performance indicates animal state of being: a Cinderella axiom? The Professional Animal Scientist 23 ( 6 ): 573 – 583 . Google Scholar CrossRef Search ADS Dash , S. , Chakravarty , A. K. , Singh , A. , Upadhyay , A. , Singh , M. and Yousuf , S. ( 2016 ). Effect of heat stress on reproductive performances of dairy cattle and buffaloes: a review . Veterinary World 9 ( 3 ): 235 – 244 . Google Scholar CrossRef Search ADS PubMed De Mey , Y. , Wauters , E. , Schmid , D. , Lips , M. , Vancauteren , M. and Van Passel , S. ( 2016 ). Farm household risk balancing: empirical evidence from Switzerland . European Review of Agricultural Economics 43 ( 4 ): 637 – 662 . Google Scholar CrossRef Search ADS Deng , X. , Barnett , B. J. , Vedenov , D. V. and West , J. W. ( 2007 ). Hedging dairy production losses using weather‐based index insurance . Agricultural Economics 36 ( 2 ): 271 – 280 . Google Scholar CrossRef Search ADS Wetterdienst , D , 2016 . FTP Server. Available at ftp://ftp.dwd.de/. Accessed 24 August 2016. Di Falco , S. and Chavas , J. P. ( 2006 ). Crop genetic diversity, farm productivity and the management of environmental risk in rainfed agriculture . European Review of Agricultural Economics 33 ( 3 ): 289 – 314 . Google Scholar CrossRef Search ADS Driscoll , P. , McGuirk , A. and Alwang , J. ( 1992 ). Testing hypotheses of functional structure: some rules for determining flexibility of restricted production models . American Journal of Agricultural Economics 74 ( 1 ): 100 – 108 . Google Scholar CrossRef Search ADS Du , X. , Yu , C. L. , Hennessy , D. A. and Miao , R. ( 2015 ). Geography of crop yield skewness . Agricultural Economics 46 : 463 – 473 . Google Scholar CrossRef Search ADS D’Antoni , J. and Mishra , A. K. ( 2012 ). Determinants of dairy farmers’ participation in the Milk Income Loss Contract program . Journal of Dairy Science 95 ( 1 ): 476 – 483 . Google Scholar CrossRef Search ADS PubMed El Benni , N. and Finger , R. ( 2013 ). Gross revenue risk in Swiss dairy farming . Journal of Dairy Science 96 ( 2 ): 936 – 948 . Google Scholar CrossRef Search ADS PubMed El Benni , N. , Finger , R. and Meuwissen , M. ( 2016 ). Potential effects of the Income Stabilization Tool (IST) in Swiss agriculture . European Review of Agricultural Economics 43 : 475 – 502 . Google Scholar CrossRef Search ADS Estrada , J. ( 2004 ). Mean-semivariance behaviour: an alternative behavioural model . Journal of Emerging Market Finance 3 ( 3 ): 231 – 248 . Google Scholar CrossRef Search ADS Estrada , J. ( 2007 ). Mean-semivariance behavior: downside risk and capital asset pricing . International Review of Economics & Finance 16 ( 2 ): 169 – 185 . Google Scholar CrossRef Search ADS Ettema , J. F. and Santos , J. E. P. ( 2004 ). Impact of age at calving on lactation, reproduction, health, and income in first-parity Holsteins on commercial farms . Journal of Dairy Science 87 ( 8 ): 2730 – 2742 . Google Scholar CrossRef Search ADS PubMed Francksen , T. , Hagemann , M. and Latacz‐Lohmann , U. ( 2012 ). Growth of milk production in German dairy farms: an empirical study based on event history analysis . Agricultural Economics 43 ( 6 ): 671 – 685 . Google Scholar CrossRef Search ADS Gatzert , N. and Kling , A. ( 2007 ). Analysis of participating life insurance contracts: a unification approach . Journal of Risk and Insurance 74 ( 3 ): 547 – 570 . Google Scholar CrossRef Search ADS Gundelach , Y. , Essmeyer , K. , Teltscher , M. K. and Hoedemaker , M. ( 2009 ). Risk factors for perinatal mortality in dairy cattle: cow and foetal factors, calving process . Theriogenology 71 ( 6 ): 901 – 909 . Google Scholar CrossRef Search ADS PubMed Hansson , H. and Lagerkvist , C. J. ( 2014 ). Decision making for animal health and welfare: integrating risk–benefit analysis with prospect theory . Risk Analysis 34 ( 6 ): 1149 – 1159 . Google Scholar CrossRef Search ADS PubMed Hare , E. H. D. N. , Norman , H. D. and Wright , J. R. ( 2006 ). Trends in calving ages and calving intervals for dairy cattle breeds in the United States . Journal of Dairy Science 89 ( 1 ): 365 – 370 . Google Scholar CrossRef Search ADS PubMed Harmon , R. J. ( 1994 ). Physiology of mastitis and factors affecting somatic cell counts . Journal of Dairy Science 77 ( 7 ): 2103 – 2112 . Google Scholar CrossRef Search ADS PubMed Haworth , G. M. , Tranter , W. P. , Chuck , J. N. , Cheng , Z. and Wathes , D. C. ( 2008 ). Relationships between age at first calving and first lactation milk yield, and lifetime productivity and longevity-in dairy cows . Veterinary Record 162 ( 20 ): 643 . Google Scholar CrossRef Search ADS PubMed Henry , G. W. , Boyer , C. N. , Griffith , A. P. , Larson , J. , Smith , A. and Lewis , K. ( 2016 ). Risk and returns of spring and fall calving for beef cattle in Tennessee . Journal of Agricultural and Applied Economics 48 ( 3 ): 257 – 278 . Google Scholar CrossRef Search ADS Hill , D. L. and Wall , E. ( 2015 ). Dairy cattle in a temperate climate: the effects of weather on milk yield and composition depend on management . Animal 9 ( 1 ): 138 – 149 . Google Scholar CrossRef Search ADS PubMed Hirsch , S. and Hartmann , M. ( 2014 ). Persistence of firm‐level profitability in the European dairy processing industry . Agricultural Economics 45 ( S1 ): 53 – 63 . Google Scholar CrossRef Search ADS Igono , M. O. , Bjotvedt , G. and Sanford-Crane , H. T. ( 1992 ). Environmental profile and critical temperature effects on milk production of Holstein cows in desert climate . International Journal of Biometeorology 36 ( 2 ): 77 – 87 . Google Scholar CrossRef Search ADS PubMed Jarrow , R. and Zhao , F. ( 2006 ). Downside loss aversion and portfolio management . Management Science 52 ( 4 ): 558 – 566 . Google Scholar CrossRef Search ADS Just , R. E. and Pope , R. D. ( 1978 ). Stochastic specification of production functions and economic implications . Journal of Economics 7 ( 1 ): 67 – 86 . Google Scholar CrossRef Search ADS Kadzere , C. T. , Murphy , M. R. , Silanikove , N. and Maltz , E. ( 2002 ). Heat stress in lactating dairy cows: a review . Livestock Production Science 77 ( 1 ): 59 – 91 . Google Scholar CrossRef Search ADS Key , N. and Sneeringer , S. ( 2014 ). Potential effects of climate change on the productivity of US dairies . American Journal of Agricultural Economics 96 ( 4 ): 1136 – 1156 . Google Scholar CrossRef Search ADS Kim , K. , Chavas , J. P. , Barham , B. and Foltz , J. ( 2014 ). Rice, irrigation and downside risk: a quantile analysis of risk exposure and mitigation on Korean farms . European Review of Agricultural Economics 41 ( 5 ): 775 – 815 . Google Scholar CrossRef Search ADS Koundouri , P. , Laukkanen , M. , Myyrä , S. and Nauges , C. ( 2009 ). The effects of EU agricultural policy changes on farmers’ risk attitudes . European Review of Agricultural Economics 36 ( 1 ): 53 – 77 . Google Scholar CrossRef Search ADS Kumbhakar , S. C. ( 1993 ). Production risk, technical efficiency, and panel data . Economic Letters 41 ( 1 ): 11 – 16 . Google Scholar CrossRef Search ADS Lawson , L. G. , Bruun , J. , Coelli , T. , Agger , J. F. and Lund , M. ( 2004 ). Relationships of efficiency to reproductive disorders in Danish milk production: a stochastic frontier analysis . Journal of dairy science 87 ( 1 ): 212 – 224 . Google Scholar CrossRef Search ADS PubMed Lusk , J. L. and Norwood , F. B. ( 2011 ). Animal welfare economics . Applied Economic Perspectives and Policy 33 ( 4 ): 463 – 483 . Google Scholar CrossRef Search ADS Marra , M. C. and Schurle , B. W. ( 1994 ). Kansas wheat yield risk measures and aggregation: a meta-analysis approach . Journal of Agricultural and Resource Economics 19 ( 1 ): 69 – 77 . McArthur , J. W. and McCord , G. C. ( 2017 ). Fertilizing growth: agricultural inputs and their effects in economic development . Journal of Development Economies 127 : 133 – 152 . Google Scholar CrossRef Search ADS Miranda , M. J. and Glauber , J. W. ( 1991 ). Providing crop disaster assistance through a modified deficiency payment program . American Journal of Agricultural Economics 73 ( 4 ): 1233 – 1243 . Google Scholar CrossRef Search ADS Müller , U. and Sauerwein , H. ( 2010 ). A comparison of somatic cell count between organic and conventional dairy cow herds in West Germany stressing dry period related changes . Livestock Science 127 ( 1 ): 30 – 37 . Google Scholar CrossRef Search ADS Musser , W. N. and Patrick , G. F. ( 2002 ). How much does risk really matter to farmers? In: Just R. E. and Pope R. D. (eds) , A Comprehensive Assessment of the Role of Risk in US Agriculture . Boston, USA : Springer , 537 – 556 . Google Scholar CrossRef Search ADS Oltenacu , P. A. and Broom , D. M. ( 2010 ). The impact of genetic selection for increased milk yield on the welfare of dairy cows . Animal Welfare 19 ( 1 ): 39 – 49 . Orea , L. and Wall , A. ( 2012 ). Productivity and producer welfare in the presence of production risk . Journal of Agricultural Economics 63 ( 1 ): 102 – 118 . Google Scholar CrossRef Search ADS Raboisson , D. , Delor , F. , Cahuzac , E. , Gendre , C. , Sans , P. and Allaire , G. ( 2013 ). Perinatal, neonatal, and rearing period mortality of dairy calves and replacement heifers in France . Journal of Dairy Science 96 ( 5 ): 2913 – 2924 . Google Scholar CrossRef Search ADS PubMed Reed , W. R. ( 2015 ). On the practice of lagging variables to avoid simultaneity . Oxford Bulletin of Economics and Statistics 77 ( 6 ): 897 – 905 . Google Scholar CrossRef Search ADS Saastamoinen , A. ( 2015 ). Heteroscedasticity or production risk? A synthetic view . Journal of Economic Surveys 29 ( 3 ): 459 – 478 . Google Scholar CrossRef Search ADS Schmit , T. M. , Boisvert , R. N. and Tauer , L. W. ( 2001 ). Measuring the financial risks of New York dairy producers . Journal of Dairy Science 84 : 411 – 420 . Google Scholar CrossRef Search ADS PubMed St-Pierre , N. R. , Cobanov , B. and Schnitkey , G. ( 2003 ). Economic loss from heat stress by US livestock industries . Journal of Dairy Science 86E ( Suppl. ): E52 – E77 . Google Scholar CrossRef Search ADS Stull , C. L. , Messam , L. M. , Collar , C. A. , Peterson , N. G. , Castillo , A. R. , Reed , B. A. , Andersen , K. L. and VerBoort , W. R. ( 2008 ). Precipitation and temperature effects on mortality and lactation parameters of dairy cattle in California . Journal of dairy science 91 ( 12 ): 4579 – 4591 . Google Scholar CrossRef Search ADS PubMed Tubiello , F. N. , Soussana , J. F. and Howden , S. M. ( 2007 ). Crop and pasture response to climate change . PNAS 104 ( 50 ): 19686 – 19690 . Google Scholar CrossRef Search ADS PubMed Tveteras , R. , Flaten , O. and Lien , G. ( 2011 ). Production risk in multi-output industries: estimates from Norwegian dairy farms . Applied Economics 43 ( 28 ): 4403 – 4414 . Google Scholar CrossRef Search ADS Valvekar , M. , Chavas , J. P. , Gould , B. W. and Cabrera , V. E. ( 2011 ). Revenue risk management, risk aversion and the use of livestock gross margin for dairy cattle insurance . Agricultural Systems 104 ( 9 ): 671 – 678 . Google Scholar CrossRef Search ADS Vedenov , D. V. and Barnett , B. J. ( 2004 ). Efficiency of weather derivatives as primary crop insurance instruments . Journal of Agricultural and Resource Economics 29 ( 3 ): 387 – 403 . Vermeulen , S. J. , Aggarwal , P. K. , Ainslie , A. , Angelone , C. , Campbell , B. M. , Challinor , A. J. , Hansen , J. W. , Ingram , J. S. I. , Jarvis , A. , Kristjanson , P. , Lau , C. , Nelson , G. C. , Thornton , P. K. and Wollenberg , E. ( 2012 ). Options for support to agriculture and food security under climate change . Environmental Science & Policy 15 ( 1 ): 136 – 144 . Google Scholar CrossRef Search ADS Vollmer , E. , Hermann , D. and Mußhoff , O. ( 2017 ). Is the risk attitude measured with the Holt and Laury task reflected in farmers’ production risk? European Review of Agricultural Economics 44 ( 3 ): 399 – 424 . Google Scholar CrossRef Search ADS Wan , G. H. and Anderson , J. R. ( 1990 ). Estimating risk effects in Chinese foodgrain production . Journal of Agricultural Economics 41 ( 1 ): 85 – 93 . Google Scholar CrossRef Search ADS Weber , S. ( 2010 ). Bacon: an effective way to detect outliers in multivariate data using Stata (and Mata) . The Stata Journal 10 ( 3 ): 331 – 338 . Wolf , C. A. , Black , R. J. and Hadrich , J. C. ( 2009 ). Upper midwest dairy farm revenue variation and insurance implications . Agricultural Finance Review 69 ( 3 ): 346 – 358 . Google Scholar CrossRef Search ADS Zellner , A. ( 1962 ). An efficient method of estimating seemingly unrelated regressions and tests for aggregation bias . Journal of the American Statistical Association 57 : 348 – 368 . Google Scholar CrossRef Search ADS Zellner , A. ( 1963 ). Estimators for seemingly unrelated regression equations: some exact finite sample results . Journal of the American Statistical Association 58 : 977 – 992 . Google Scholar CrossRef Search ADS Zellner , A. and Huang , D. S. ( 1962 ). Further properties of efficient estimators for seemingly unrelated regression equations . International Economic Review 3 : 300 – 313 . Google Scholar CrossRef Search ADS Appendix Table A1. Correlations of inputs and outputs 1 2 3 4 5 6 7 8 9 10 11 12 13 1 2 0.781 3 0.518 0.408 4 0.865 0.719 0.540 5 0.930 0.770 0.450 0.816 6 0.825 0.715 0.625 0.807 0.805 7 0.910 0.755 0.488 0.804 0.887 0.790 8 0.069 0.049 0.042 0.046 0.094 0.116 0.068 9 −0.052 −0.109 −0.003 −0.070 −0.027 −0.019 −0.039 0.140 10 −0.011 −0.009 −0.123 −0.034 0.019 −0.022 −0.015 0.105 0.074 11 0.095 0.148 −0.005 0.103 0.166 0.154 0.184 0.092 0.009 0.045 12 0.936 0.772 0.532 0.875 0.892 0.843 0.881 0.070 −0.043 −0.006 0.159 13 −0.211 −0.191 0.131 −0.160 −0.250 −0.086 −0.216 0.044 0.078 −0.061 −0.143 −0.199 14 0.109 0.165 −0.060 0.090 0.196 0.087 0.216 0.004 0.028 0.077 0.115 0.105 −0.254 1 2 3 4 5 6 7 8 9 10 11 12 13 1 2 0.781 3 0.518 0.408 4 0.865 0.719 0.540 5 0.930 0.770 0.450 0.816 6 0.825 0.715 0.625 0.807 0.805 7 0.910 0.755 0.488 0.804 0.887 0.790 8 0.069 0.049 0.042 0.046 0.094 0.116 0.068 9 −0.052 −0.109 −0.003 −0.070 −0.027 −0.019 −0.039 0.140 10 −0.011 −0.009 −0.123 −0.034 0.019 −0.022 −0.015 0.105 0.074 11 0.095 0.148 −0.005 0.103 0.166 0.154 0.184 0.092 0.009 0.045 12 0.936 0.772 0.532 0.875 0.892 0.843 0.881 0.070 −0.043 −0.006 0.159 13 −0.211 −0.191 0.131 −0.160 −0.250 −0.086 −0.216 0.044 0.078 −0.061 −0.143 −0.199 14 0.109 0.165 −0.060 0.090 0.196 0.087 0.216 0.004 0.028 0.077 0.115 0.105 −0.254 Note: Variable numbers as defined in Table 1. Table A1. Correlations of inputs and outputs 1 2 3 4 5 6 7 8 9 10 11 12 13 1 2 0.781 3 0.518 0.408 4 0.865 0.719 0.540 5 0.930 0.770 0.450 0.816 6 0.825 0.715 0.625 0.807 0.805 7 0.910 0.755 0.488 0.804 0.887 0.790 8 0.069 0.049 0.042 0.046 0.094 0.116 0.068 9 −0.052 −0.109 −0.003 −0.070 −0.027 −0.019 −0.039 0.140 10 −0.011 −0.009 −0.123 −0.034 0.019 −0.022 −0.015 0.105 0.074 11 0.095 0.148 −0.005 0.103 0.166 0.154 0.184 0.092 0.009 0.045 12 0.936 0.772 0.532 0.875 0.892 0.843 0.881 0.070 −0.043 −0.006 0.159 13 −0.211 −0.191 0.131 −0.160 −0.250 −0.086 −0.216 0.044 0.078 −0.061 −0.143 −0.199 14 0.109 0.165 −0.060 0.090 0.196 0.087 0.216 0.004 0.028 0.077 0.115 0.105 −0.254 1 2 3 4 5 6 7 8 9 10 11 12 13 1 2 0.781 3 0.518 0.408 4 0.865 0.719 0.540 5 0.930 0.770 0.450 0.816 6 0.825 0.715 0.625 0.807 0.805 7 0.910 0.755 0.488 0.804 0.887 0.790 8 0.069 0.049 0.042 0.046 0.094 0.116 0.068 9 −0.052 −0.109 −0.003 −0.070 −0.027 −0.019 −0.039 0.140 10 −0.011 −0.009 −0.123 −0.034 0.019 −0.022 −0.015 0.105 0.074 11 0.095 0.148 −0.005 0.103 0.166 0.154 0.184 0.092 0.009 0.045 12 0.936 0.772 0.532 0.875 0.892 0.843 0.881 0.070 −0.043 −0.006 0.159 13 −0.211 −0.191 0.131 −0.160 −0.250 −0.086 −0.216 0.044 0.078 −0.061 −0.143 −0.199 14 0.109 0.165 −0.060 0.090 0.196 0.087 0.216 0.004 0.028 0.077 0.115 0.105 −0.254 Note: Variable numbers as defined in Table 1. Table A2. First-stage regression results of 2SLS mean functions Independent variables Animal losses Dead births Somatic cell count Exogeneous regressors Land −0.022 −0.032* −0.347 (0.015) (0.019) (0.254) Labour −0.001** −0.001** −0.008** (0.000) (0.000) (0.004) Feed −0.000* −0.000 −0.000 (0.000) (0.000) (0.000) Number of cattle −0.002 0.014* −0.007 (0.006) (0.008) (0.085) Costs 0.000 −0.000 0.000*** (0.000) (0.000) (0.000) Land × Land 0.000 0.000 0.002* (0.000) (0.000) (0.001) Labour × Labour 0.000 0.000 −0.000 (0.000) (0.000) (0.000) Feed × Feed −0.000 0.000 −0.000* (0.000) (0.000) (0.000) Number of Cattle × Number of Cattle 0.000 −0.000 0.000 (0.000) (0.000) (0.000) Costs × Costs −0.000 0.000** −0.000* (0.000) (0.000) (0.000) Land × Labour 0.000*** 0.000* 0.000 (0.000) (0.000) (0.000) Land × Feed 0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Land × Number of Cattle −0.000 −0.000 −0.000 (0.000) (0.000) (0.001) Land × Costs −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Feed −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Number of Cattle −0.000 −0.000 0.000 (0.000) (0.000) (0.000) Labour × Costs −0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Feed × Number of Cattle 0.000 0.000 0.000 (0.000) (0.000) (0.000) Feed × Costs 0.000 −0.000* 0.000** (0.000) (0.000) (0.000) Number of Cattle × Costs −0.000 0.000 −0.000 (0.000) (0.000) (0.000) THI Load 75 −0.006 0.008 −0.036 (0.004) (0.005) (0.052) Milk quota 0.000*** 0.000 −0.000 (0.000) (0.000) (0.000) Instruments First calving age t−1 0.066 −0.104 −0.163 (0.045) (0.065) (0.555) Somatic cell count t−1 0.004** 0.003 0.222*** (0.002) (0.002) (0.027) Animal losses t−1 −0.096*** −0.037 0.591** (0.027) (0.033) (0.293) Dead births t−1 0.003 0.091*** 0.114 (0.016) (0.032) (0.209) Veterinary expenditure t−1 −0.003 −0.003 −0.034 (0.002) (0.003) (0.031) Fa 12.81 24.59 20.70 p-value 0.000 0.000 0.000 Adjusted R2 0.355 0.373 0.629 n 2,630 2,630 2,630 Independent variables Animal losses Dead births Somatic cell count Exogeneous regressors Land −0.022 −0.032* −0.347 (0.015) (0.019) (0.254) Labour −0.001** −0.001** −0.008** (0.000) (0.000) (0.004) Feed −0.000* −0.000 −0.000 (0.000) (0.000) (0.000) Number of cattle −0.002 0.014* −0.007 (0.006) (0.008) (0.085) Costs 0.000 −0.000 0.000*** (0.000) (0.000) (0.000) Land × Land 0.000 0.000 0.002* (0.000) (0.000) (0.001) Labour × Labour 0.000 0.000 −0.000 (0.000) (0.000) (0.000) Feed × Feed −0.000 0.000 −0.000* (0.000) (0.000) (0.000) Number of Cattle × Number of Cattle 0.000 −0.000 0.000 (0.000) (0.000) (0.000) Costs × Costs −0.000 0.000** −0.000* (0.000) (0.000) (0.000) Land × Labour 0.000*** 0.000* 0.000 (0.000) (0.000) (0.000) Land × Feed 0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Land × Number of Cattle −0.000 −0.000 −0.000 (0.000) (0.000) (0.001) Land × Costs −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Feed −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Number of Cattle −0.000 −0.000 0.000 (0.000) (0.000) (0.000) Labour × Costs −0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Feed × Number of Cattle 0.000 0.000 0.000 (0.000) (0.000) (0.000) Feed × Costs 0.000 −0.000* 0.000** (0.000) (0.000) (0.000) Number of Cattle × Costs −0.000 0.000 −0.000 (0.000) (0.000) (0.000) THI Load 75 −0.006 0.008 −0.036 (0.004) (0.005) (0.052) Milk quota 0.000*** 0.000 −0.000 (0.000) (0.000) (0.000) Instruments First calving age t−1 0.066 −0.104 −0.163 (0.045) (0.065) (0.555) Somatic cell count t−1 0.004** 0.003 0.222*** (0.002) (0.002) (0.027) Animal losses t−1 −0.096*** −0.037 0.591** (0.027) (0.033) (0.293) Dead births t−1 0.003 0.091*** 0.114 (0.016) (0.032) (0.209) Veterinary expenditure t−1 −0.003 −0.003 −0.034 (0.002) (0.003) (0.031) Fa 12.81 24.59 20.70 p-value 0.000 0.000 0.000 Adjusted R2 0.355 0.373 0.629 n 2,630 2,630 2,630 Note: Dependent variable is somatic cell count. Standard errors in parentheses. ***, ** and * indicate significance at the 10, 5 and 1 per cent level, respectively. aRefers to the general F-test of the first-stage regression. Table A2. First-stage regression results of 2SLS mean functions Independent variables Animal losses Dead births Somatic cell count Exogeneous regressors Land −0.022 −0.032* −0.347 (0.015) (0.019) (0.254) Labour −0.001** −0.001** −0.008** (0.000) (0.000) (0.004) Feed −0.000* −0.000 −0.000 (0.000) (0.000) (0.000) Number of cattle −0.002 0.014* −0.007 (0.006) (0.008) (0.085) Costs 0.000 −0.000 0.000*** (0.000) (0.000) (0.000) Land × Land 0.000 0.000 0.002* (0.000) (0.000) (0.001) Labour × Labour 0.000 0.000 −0.000 (0.000) (0.000) (0.000) Feed × Feed −0.000 0.000 −0.000* (0.000) (0.000) (0.000) Number of Cattle × Number of Cattle 0.000 −0.000 0.000 (0.000) (0.000) (0.000) Costs × Costs −0.000 0.000** −0.000* (0.000) (0.000) (0.000) Land × Labour 0.000*** 0.000* 0.000 (0.000) (0.000) (0.000) Land × Feed 0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Land × Number of Cattle −0.000 −0.000 −0.000 (0.000) (0.000) (0.001) Land × Costs −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Feed −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Number of Cattle −0.000 −0.000 0.000 (0.000) (0.000) (0.000) Labour × Costs −0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Feed × Number of Cattle 0.000 0.000 0.000 (0.000) (0.000) (0.000) Feed × Costs 0.000 −0.000* 0.000** (0.000) (0.000) (0.000) Number of Cattle × Costs −0.000 0.000 −0.000 (0.000) (0.000) (0.000) THI Load 75 −0.006 0.008 −0.036 (0.004) (0.005) (0.052) Milk quota 0.000*** 0.000 −0.000 (0.000) (0.000) (0.000) Instruments First calving age t−1 0.066 −0.104 −0.163 (0.045) (0.065) (0.555) Somatic cell count t−1 0.004** 0.003 0.222*** (0.002) (0.002) (0.027) Animal losses t−1 −0.096*** −0.037 0.591** (0.027) (0.033) (0.293) Dead births t−1 0.003 0.091*** 0.114 (0.016) (0.032) (0.209) Veterinary expenditure t−1 −0.003 −0.003 −0.034 (0.002) (0.003) (0.031) Fa 12.81 24.59 20.70 p-value 0.000 0.000 0.000 Adjusted R2 0.355 0.373 0.629 n 2,630 2,630 2,630 Independent variables Animal losses Dead births Somatic cell count Exogeneous regressors Land −0.022 −0.032* −0.347 (0.015) (0.019) (0.254) Labour −0.001** −0.001** −0.008** (0.000) (0.000) (0.004) Feed −0.000* −0.000 −0.000 (0.000) (0.000) (0.000) Number of cattle −0.002 0.014* −0.007 (0.006) (0.008) (0.085) Costs 0.000 −0.000 0.000*** (0.000) (0.000) (0.000) Land × Land 0.000 0.000 0.002* (0.000) (0.000) (0.001) Labour × Labour 0.000 0.000 −0.000 (0.000) (0.000) (0.000) Feed × Feed −0.000 0.000 −0.000* (0.000) (0.000) (0.000) Number of Cattle × Number of Cattle 0.000 −0.000 0.000 (0.000) (0.000) (0.000) Costs × Costs −0.000 0.000** −0.000* (0.000) (0.000) (0.000) Land × Labour 0.000*** 0.000* 0.000 (0.000) (0.000) (0.000) Land × Feed 0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Land × Number of Cattle −0.000 −0.000 −0.000 (0.000) (0.000) (0.001) Land × Costs −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Feed −0.000 0.000 0.000 (0.000) (0.000) (0.000) Labour × Number of Cattle −0.000 −0.000 0.000 (0.000) (0.000) (0.000) Labour × Costs −0.000 −0.000 −0.000 (0.000) (0.000) (0.000) Feed × Number of Cattle 0.000 0.000 0.000 (0.000) (0.000) (0.000) Feed × Costs 0.000 −0.000* 0.000** (0.000) (0.000) (0.000) Number of Cattle × Costs −0.000 0.000 −0.000 (0.000) (0.000) (0.000) THI Load 75 −0.006 0.008 −0.036 (0.004) (0.005) (0.052) Milk quota 0.000*** 0.000 −0.000 (0.000) (0.000) (0.000) Instruments First calving age t−1 0.066 −0.104 −0.163 (0.045) (0.065) (0.555) Somatic cell count t−1 0.004** 0.003 0.222*** (0.002) (0.002) (0.027) Animal losses t−1 −0.096*** −0.037 0.591** (0.027) (0.033) (0.293) Dead births t−1 0.003 0.091*** 0.114 (0.016) (0.032) (0.209) Veterinary expenditure t−1 −0.003 −0.003 −0.034 (0.002) (0.003) (0.031) Fa 12.81 24.59 20.70 p-value 0.000 0.000 0.000 Adjusted R2 0.355 0.373 0.629 n 2,630 2,630 2,630 Note: Dependent variable is somatic cell count. Standard errors in parentheses. ***, ** and * indicate significance at the 10, 5 and 1 per cent level, respectively. aRefers to the general F-test of the first-stage regression. Table A3. Input elasticity estimates and regression coefficients for THI, milk quota and animal health factors with interaction terms Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.099 0.773** −0.097 −0.37 0.542* (0.037) (0.331) (0.129) (0.267) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.33*** 0.871 0.338*** 0.283 0.958* (0.033) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) 0.509 (0.661) Costs 0.119*** 0.472 −0.092 0.127 0.156 (0.023) (0.576) (0.071) (0.879) (0.460) Regression coefficients Somatic cell count −228.15** −59,21,950*** 4.181 −1,57,257.3* −4,18,419.6 (98.711) (22,15,541) (31.599) (95,083.88) (3,50,538.2) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (18,28,590) (78,11,891) Dead births 250.048 6.08e7** −433.959 −9,85,138 55,38,159 (1,893.67) (2.66e7) (563.841) (10,30,456) (44,49,029) THI Load 75 −167.361*** 28,36,334 10.251 3,88,200.6* 6,85,842.3 (51.782) (55,47,605) (16.577) (2,10,491.4) (7,75,890.9) Milk quota 0.103*** 1,553.617 0.001 83.804 234.587 (0.027) (1,443.749) (0.005) (63.736) (193.063) Land × Land 0.150 −2,43,703.000 −0.104 −4,657.853 −30,966.780* (1.051) (1,55,582.900) (0.308) (4,029.839) (16,189.180) Labour × Labour −0.000 125.038 0.001** 14.628** 42.955* (0.001) (139.790) (0.000) (6.327) (23.783) Feed × Feed −0.000* −1.238** 0.000 0.018 −0.195*** (0.000) (0.532) (0.000) (0.017) (0.058) Number of Cattle × Number of Cattle −0.167 2,57,953.200** 0.086 1,334.746 33,216.260*** (0.567) (1,17,803.800) (0.154) (1,914.600) (11,619.460) Costs × Costs 0.000 −0.438* 0.000*** 0.047** −0.012 (0.000) (0.266) (0.000) (0.023) (0.032) Land × Labour −0.069 −17,523.210** −0.050** −292.844 −2,813.138** (0.087) (8,905.824) (0.021) (305.788) (1,257.922) Land × Feed −0.001 575.677* −0.001* −20.755 65.654 (0.002) (297.328) (0.001) (16.110) (41.961) Land × Number of Cattle 3.181** 6,74,292.900*** 1.523*** 8311.294 49,069.110** (1.586) (2,55,317.200) (0.406) (5,500.180) (22,297.740) Land × Costs −0.003 −838.172** −0.000 12.964 −33.239 (0.002) (374.772) (0.001) (14.105) (42.485) Labour × Feed 0.000*** −5.076 0.000 0.980* 4.108*** (0.000) (9.673) (0.000) (0.589) (1.532) Labour × Number of Cattle −0.058 −6,003.888 −0.022 −213.063 −875.302 (0.049) (4,877.211) (0.015) (172.843) (724.999) Labour × Costs −0.000 6.221 −0.000 −1.319* −2.714 (0.000) (10.394) (0.000) (0.677) (1.762) Feed × Number of Cattle −0.001 1,37,686 −0.000 −7.933 −23.071 (0.002) (282.787) (0.000) (8.644) (38.122) Feed × Costs −0.000 1.771** −0.000 −0.059* 0.205** (0.000) (0.856) (0.000) (0.034) (0.093) Number of Cattle × Costs 0.004*** −439.918* −0.001 9.567 −37.854 (0.001) (247.164) (0.000) (7.468) (25.925) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 0.000 0.000 p-value Sargan χ2 1.473 0.064 p-value 0.479 1,706 0.969 1,573 1,001 n 2,630 2,630 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.099 0.773** −0.097 −0.37 0.542* (0.037) (0.331) (0.129) (0.267) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.33*** 0.871 0.338*** 0.283 0.958* (0.033) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) 0.509 (0.661) Costs 0.119*** 0.472 −0.092 0.127 0.156 (0.023) (0.576) (0.071) (0.879) (0.460) Regression coefficients Somatic cell count −228.15** −59,21,950*** 4.181 −1,57,257.3* −4,18,419.6 (98.711) (22,15,541) (31.599) (95,083.88) (3,50,538.2) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (18,28,590) (78,11,891) Dead births 250.048 6.08e7** −433.959 −9,85,138 55,38,159 (1,893.67) (2.66e7) (563.841) (10,30,456) (44,49,029) THI Load 75 −167.361*** 28,36,334 10.251 3,88,200.6* 6,85,842.3 (51.782) (55,47,605) (16.577) (2,10,491.4) (7,75,890.9) Milk quota 0.103*** 1,553.617 0.001 83.804 234.587 (0.027) (1,443.749) (0.005) (63.736) (193.063) Land × Land 0.150 −2,43,703.000 −0.104 −4,657.853 −30,966.780* (1.051) (1,55,582.900) (0.308) (4,029.839) (16,189.180) Labour × Labour −0.000 125.038 0.001** 14.628** 42.955* (0.001) (139.790) (0.000) (6.327) (23.783) Feed × Feed −0.000* −1.238** 0.000 0.018 −0.195*** (0.000) (0.532) (0.000) (0.017) (0.058) Number of Cattle × Number of Cattle −0.167 2,57,953.200** 0.086 1,334.746 33,216.260*** (0.567) (1,17,803.800) (0.154) (1,914.600) (11,619.460) Costs × Costs 0.000 −0.438* 0.000*** 0.047** −0.012 (0.000) (0.266) (0.000) (0.023) (0.032) Land × Labour −0.069 −17,523.210** −0.050** −292.844 −2,813.138** (0.087) (8,905.824) (0.021) (305.788) (1,257.922) Land × Feed −0.001 575.677* −0.001* −20.755 65.654 (0.002) (297.328) (0.001) (16.110) (41.961) Land × Number of Cattle 3.181** 6,74,292.900*** 1.523*** 8311.294 49,069.110** (1.586) (2,55,317.200) (0.406) (5,500.180) (22,297.740) Land × Costs −0.003 −838.172** −0.000 12.964 −33.239 (0.002) (374.772) (0.001) (14.105) (42.485) Labour × Feed 0.000*** −5.076 0.000 0.980* 4.108*** (0.000) (9.673) (0.000) (0.589) (1.532) Labour × Number of Cattle −0.058 −6,003.888 −0.022 −213.063 −875.302 (0.049) (4,877.211) (0.015) (172.843) (724.999) Labour × Costs −0.000 6.221 −0.000 −1.319* −2.714 (0.000) (10.394) (0.000) (0.677) (1.762) Feed × Number of Cattle −0.001 1,37,686 −0.000 −7.933 −23.071 (0.002) (282.787) (0.000) (8.644) (38.122) Feed × Costs −0.000 1.771** −0.000 −0.059* 0.205** (0.000) (0.856) (0.000) (0.034) (0.093) Number of Cattle × Costs 0.004*** −439.918* −0.001 9.567 −37.854 (0.001) (247.164) (0.000) (7.468) (25.925) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 0.000 0.000 p-value Sargan χ2 1.473 0.064 p-value 0.479 1,706 0.969 1,573 1,001 n 2,630 2,630 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Note: Values for inputs (land, labour, feed, number of cattle and costs) are output elasticities w.r.t. those inputs; values for somatic cell count, calving age, THI load 75 and milk quota are regression coefficients. Heteroskedasticity robust standard errors in parentheses. *, ** and *** indicate significance at the 10, 5 and 1 per cent level, respectively. Table A3. Input elasticity estimates and regression coefficients for THI, milk quota and animal health factors with interaction terms Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.099 0.773** −0.097 −0.37 0.542* (0.037) (0.331) (0.129) (0.267) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.33*** 0.871 0.338*** 0.283 0.958* (0.033) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) 0.509 (0.661) Costs 0.119*** 0.472 −0.092 0.127 0.156 (0.023) (0.576) (0.071) (0.879) (0.460) Regression coefficients Somatic cell count −228.15** −59,21,950*** 4.181 −1,57,257.3* −4,18,419.6 (98.711) (22,15,541) (31.599) (95,083.88) (3,50,538.2) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (18,28,590) (78,11,891) Dead births 250.048 6.08e7** −433.959 −9,85,138 55,38,159 (1,893.67) (2.66e7) (563.841) (10,30,456) (44,49,029) THI Load 75 −167.361*** 28,36,334 10.251 3,88,200.6* 6,85,842.3 (51.782) (55,47,605) (16.577) (2,10,491.4) (7,75,890.9) Milk quota 0.103*** 1,553.617 0.001 83.804 234.587 (0.027) (1,443.749) (0.005) (63.736) (193.063) Land × Land 0.150 −2,43,703.000 −0.104 −4,657.853 −30,966.780* (1.051) (1,55,582.900) (0.308) (4,029.839) (16,189.180) Labour × Labour −0.000 125.038 0.001** 14.628** 42.955* (0.001) (139.790) (0.000) (6.327) (23.783) Feed × Feed −0.000* −1.238** 0.000 0.018 −0.195*** (0.000) (0.532) (0.000) (0.017) (0.058) Number of Cattle × Number of Cattle −0.167 2,57,953.200** 0.086 1,334.746 33,216.260*** (0.567) (1,17,803.800) (0.154) (1,914.600) (11,619.460) Costs × Costs 0.000 −0.438* 0.000*** 0.047** −0.012 (0.000) (0.266) (0.000) (0.023) (0.032) Land × Labour −0.069 −17,523.210** −0.050** −292.844 −2,813.138** (0.087) (8,905.824) (0.021) (305.788) (1,257.922) Land × Feed −0.001 575.677* −0.001* −20.755 65.654 (0.002) (297.328) (0.001) (16.110) (41.961) Land × Number of Cattle 3.181** 6,74,292.900*** 1.523*** 8311.294 49,069.110** (1.586) (2,55,317.200) (0.406) (5,500.180) (22,297.740) Land × Costs −0.003 −838.172** −0.000 12.964 −33.239 (0.002) (374.772) (0.001) (14.105) (42.485) Labour × Feed 0.000*** −5.076 0.000 0.980* 4.108*** (0.000) (9.673) (0.000) (0.589) (1.532) Labour × Number of Cattle −0.058 −6,003.888 −0.022 −213.063 −875.302 (0.049) (4,877.211) (0.015) (172.843) (724.999) Labour × Costs −0.000 6.221 −0.000 −1.319* −2.714 (0.000) (10.394) (0.000) (0.677) (1.762) Feed × Number of Cattle −0.001 1,37,686 −0.000 −7.933 −23.071 (0.002) (282.787) (0.000) (8.644) (38.122) Feed × Costs −0.000 1.771** −0.000 −0.059* 0.205** (0.000) (0.856) (0.000) (0.034) (0.093) Number of Cattle × Costs 0.004*** −439.918* −0.001 9.567 −37.854 (0.001) (247.164) (0.000) (7.468) (25.925) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 0.000 0.000 p-value Sargan χ2 1.473 0.064 p-value 0.479 1,706 0.969 1,573 1,001 n 2,630 2,630 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Milk Animal sales Inputs/control variables Mean Semi-variance Mean Semi-variance Semi-covariance Elasticities Land −0.099 0.773** −0.097 −0.37 0.542* (0.037) (0.331) (0.129) (0.267) (0.291) Labour 0.113*** 0.519 0.029 −1.011* −0.615 (0.029) (0.533) (0.093) (0.569) (0.475) Feed 0.33*** 0.871 0.338*** 0.283 0.958* (0.033) (0.609) (0.084) (0.673) (0.563) Number of cattle 0.161*** −2.838 ** 0.219 1.126** −0.872 (0.045) (1.393) (0.153) 0.509 (0.661) Costs 0.119*** 0.472 −0.092 0.127 0.156 (0.023) (0.576) (0.071) (0.879) (0.460) Regression coefficients Somatic cell count −228.15** −59,21,950*** 4.181 −1,57,257.3* −4,18,419.6 (98.711) (22,15,541) (31.599) (95,083.88) (3,50,538.2) Animal losses 5,821.383** 3.29e8*** 1,772.818** 1.18e7*** 5.94e7*** (2,494.783) (3.98e7) (760.881) (18,28,590) (78,11,891) Dead births 250.048 6.08e7** −433.959 −9,85,138 55,38,159 (1,893.67) (2.66e7) (563.841) (10,30,456) (44,49,029) THI Load 75 −167.361*** 28,36,334 10.251 3,88,200.6* 6,85,842.3 (51.782) (55,47,605) (16.577) (2,10,491.4) (7,75,890.9) Milk quota 0.103*** 1,553.617 0.001 83.804 234.587 (0.027) (1,443.749) (0.005) (63.736) (193.063) Land × Land 0.150 −2,43,703.000 −0.104 −4,657.853 −30,966.780* (1.051) (1,55,582.900) (0.308) (4,029.839) (16,189.180) Labour × Labour −0.000 125.038 0.001** 14.628** 42.955* (0.001) (139.790) (0.000) (6.327) (23.783) Feed × Feed −0.000* −1.238** 0.000 0.018 −0.195*** (0.000) (0.532) (0.000) (0.017) (0.058) Number of Cattle × Number of Cattle −0.167 2,57,953.200** 0.086 1,334.746 33,216.260*** (0.567) (1,17,803.800) (0.154) (1,914.600) (11,619.460) Costs × Costs 0.000 −0.438* 0.000*** 0.047** −0.012 (0.000) (0.266) (0.000) (0.023) (0.032) Land × Labour −0.069 −17,523.210** −0.050** −292.844 −2,813.138** (0.087) (8,905.824) (0.021) (305.788) (1,257.922) Land × Feed −0.001 575.677* −0.001* −20.755 65.654 (0.002) (297.328) (0.001) (16.110) (41.961) Land × Number of Cattle 3.181** 6,74,292.900*** 1.523*** 8311.294 49,069.110** (1.586) (2,55,317.200) (0.406) (5,500.180) (22,297.740) Land × Costs −0.003 −838.172** −0.000 12.964 −33.239 (0.002) (374.772) (0.001) (14.105) (42.485) Labour × Feed 0.000*** −5.076 0.000 0.980* 4.108*** (0.000) (9.673) (0.000) (0.589) (1.532) Labour × Number of Cattle −0.058 −6,003.888 −0.022 −213.063 −875.302 (0.049) (4,877.211) (0.015) (172.843) (724.999) Labour × Costs −0.000 6.221 −0.000 −1.319* −2.714 (0.000) (10.394) (0.000) (0.677) (1.762) Feed × Number of Cattle −0.001 1,37,686 −0.000 −7.933 −23.071 (0.002) (282.787) (0.000) (8.644) (38.122) Feed × Costs −0.000 1.771** −0.000 −0.059* 0.205** (0.000) (0.856) (0.000) (0.034) (0.093) Number of Cattle × Costs 0.004*** −439.918* −0.001 9.567 −37.854 (0.001) (247.164) (0.000) (7.468) (25.925) F 25.340 5.220 9.340 p-value 0.000 0.000 0.000 Wald χ2 80281.48 8041.70 0.000 0.000 p-value Sargan χ2 1.473 0.064 p-value 0.479 1,706 0.969 1,573 1,001 n 2,630 2,630 First-stage statistics Minimum eigenvalue statistic 4.607 4.607 Critical value 4.300 4.300 Note: Values for inputs (land, labour, feed, number of cattle and costs) are output elasticities w.r.t. those inputs; values for somatic cell count, calving age, THI load 75 and milk quota are regression coefficients. Heteroskedasticity robust standard errors in parentheses. *, ** and *** indicate significance at the 10, 5 and 1 per cent level, respectively. Fig. A1. View largeDownload slide Location of farms. Fig. A1. View largeDownload slide Location of farms. Fig. A2. View largeDownload slide THI load for the years 2007–2014. Fig. A2. View largeDownload slide THI load for the years 2007–2014. Fig. A3. View largeDownload slide View largeDownload slide Impact of inputs on expected revenues (absolute effects) and semi-variance (marginal effects) of milk production and animal sales. Fig. A3. View largeDownload slide View largeDownload slide Impact of inputs on expected revenues (absolute effects) and semi-variance (marginal effects) of milk production and animal sales. Author notes Review coordinated by Jack Peerlings © Oxford University Press and Foundation for the European Review of Agricultural Economics 2018; all rights reserved. For permissions, please e-mail: journals.permissions@oup.com This article is published and distributed under the terms of the Oxford University Press, Standard Journals Publication Model (https://academic.oup.com/journals/pages/about_us/legal/notices)

European Review of Agricultural Economics – Oxford University Press

**Published: ** Sep 1, 2018

Loading...

personal research library

It’s your single place to instantly

**discover** and **read** the research

that matters to you.

Enjoy **affordable access** to

over 18 million articles from more than

**15,000 peer-reviewed journals**.

All for just $49/month

Query the DeepDyve database, plus search all of PubMed and Google Scholar seamlessly

Save any article or search result from DeepDyve, PubMed, and Google Scholar... all in one place.

Get unlimited, online access to over 18 million full-text articles from more than 15,000 scientific journals.

Read from thousands of the leading scholarly journals from *SpringerNature*, *Elsevier*, *Wiley-Blackwell*, *Oxford University Press* and more.

All the latest content is available, no embargo periods.

## “Hi guys, I cannot tell you how much I love this resource. Incredible. I really believe you've hit the nail on the head with this site in regards to solving the research-purchase issue.”

Daniel C.

## “Whoa! It’s like Spotify but for academic articles.”

@Phil_Robichaud

## “I must say, @deepdyve is a fabulous solution to the independent researcher's problem of #access to #information.”

@deepthiw

## “My last article couldn't be possible without the platform @deepdyve that makes journal papers cheaper.”

@JoseServera

DeepDyve ## Freelancer | DeepDyve ## Pro | |
---|---|---|

Price | FREE | $49/month |

Save searches from | ||

Create folders to | ||

Export folders, citations | ||

Read DeepDyve articles | Abstract access only | Unlimited access to over |

20 pages / month | ||

PDF Discount | 20% off | |

Read and print from thousands of top scholarly journals.

System error. Please try again!

Already have an account? Log in

Bookmark this article. You can see your Bookmarks on your DeepDyve Library.

To save an article, **log in** first, or **sign up** for a DeepDyve account if you don’t already have one.

Copy and paste the desired citation format or use the link below to download a file formatted for EndNote

**EndNote**

All DeepDyve websites use cookies to improve your online experience. They were placed on your computer when you launched this website. You can change your cookie settings through your browser.

ok to continue