European Review of Agricultural Economics, Volume Advance Article (3) – Mar 15, 2018

29 pages

/lp/ou_press/effect-of-family-labour-on-output-of-farms-in-selected-eu-member-Q5sedltEui

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- Oxford University Press
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- © 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.
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- 0165-1587
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- 1464-3618
- D.O.I.
- 10.1093/erae/jbx036
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Abstract There is very little empirical evidence supporting the claims that family farming is a ‘superior’ form of organisation for agricultural production. This paper investigates the comparative output effects of family labour in several EU Member States. No positive output effects can be discerned when farms are characterised by a low level of technical efficiency. In the case of efficient farms, the incremental effects of family labour are characterised by a number of thresholds. The paper only finds limited support for the claimed positive output effects of family farming and these only materialise after a considerable family involvement is committed. 1. Introduction The United Nations (UN) announced 2014 as the International Year of Family Farming (IYFF) with the objective of this world-wide initiative to draw attention to the multiple roles played by family farming. The regional and global events, organised within the IYFF, supported strongly the claims of the ‘superiority’ of agriculture organised by family farms in contrast to the non-family ‘corporate'1 form of organisation of farming. The debate gave prominence to the family values sustained by the family farming and the social functions these may generate. The FAO, for example, emphasised that the family and the farm are linked through co-evolution that provides a combination of economic, environmental, social and cultural functions (FAO, 2013). Beyond the social and the cultural functions, however, the perceived economic strengths of family farms were debated in the absence of supporting empirical evidence. This high level of international attention clearly calls for more rigorous analysis in order to properly inform this debate. In the EU, family farming has been a target for the Common Agricultural Policy (CAP) since its inception. Through instruments of market price support in the past and through the CAP Pillar 1 decoupled direct payments in recent decades, large transfers from consumers and taxpayers to family farms have taken place although, of course, other farm structures have benefitted immensely too. The effects of this support have been far-reaching and complex (Hennessy, 2014). Overall, the CAP maintained many inefficient family farms in business and slowed down structural change. The theoretical arguments related to the superiority, or otherwise, of family farming are twofold. On the one hand, an argument centred on the relative transaction costs associated with the employment of family and hired labour is often used. This argument asserts that family labour could be more productive and require lower monitoring costs due to the incentive compatibility because these workers are a residual claimant on farm profits (Pollak, 1985; Allen and Lueck, 1998). The spatial dispersion of work tasks, which is often pronounced in agriculture, is argued to make these monitoring and motivation costs particularly large. This effect may extend to farms which employ both family and hired workers simply because effective monitoring of hired workers is greater, increasing the productivity of hired workers above a level observed in the absence of family members. This implies that the average productivity of labour on family farms might be larger when compared to workers on wholly hired labour employing corporate farms. This is termed in this paper as the ‘motivation hypothesis’. Allen and Lueck (1998) define the conditions under which the family farm is a better form of organisation in comparison to the corporate farms. These can be divided into three groups: specialisation, seasonality and monitoring. More specifically, family farms are more likely to be a predominant form if there is: (1) less scope for specialisation (i.e. lower returns to specialisation) and a production process with smaller number of tasks; (2) shorter length of the production stages; (3) smaller number of production cycles; (4) higher probability of production shocks, high output variation and uncertainty, and (5) higher monitoring costs. Conditions 1–3 are related to the returns to specialisation, conditions 3 and 4 refer to seasonality, while condition 5 clearly spells out the role of monitoring. In essence, the superiority of family farms manifests itself when standard monitoring mechanisms fail to achieve their purpose due to the peculiarities of agricultural production. The transaction costs approach suggests that, due to different incentives and information asymmetries, family and non-family labour have to be distinguished as they are not perfect substitutes in production. In defining the overall potential effect of family farming, Pollak (1985) also emphasises ‘social’ antecedents like altruism and loyalty which have the potential to promote productivity on family farms. Family farms may take a long-term interest in preserving the farm and land fertility for the next generations which may also promote the economic sustainability of the farm. However, on the other hand, Pollak (1985) also noted a number of potentially negative forces associated with family employment such as nepotism and size limitations, and sometimes family labour may lack entrepreneurial spirit and other specialised skills. The engagement of family labour could simply act as a way to find employment for family members due to the lack of alternative job opportunities in rural areas and/or low opportunity costs, and as a means to preserve family traditions and values. This may lead to under-employment, drive down the marginal product of labour used and undermine farm efficiency. By the same token, family labour may not possess the specialised skills, talent and entrepreneurial spirit required by modern farm management, because workers are drawn from a restricted pool of labour. This might lead to a situation in which, once a farm becomes more family oriented, the incremental contribution to output would decrease. This effect is denoted in the study as the ‘management capabilities deterioration hypothesis’. Therefore, despite the theoretical assertions based on the transaction cost argument, it cannot be assumed a priori that family labour has necessarily a positive production impact as there are two potentially opposing mechanisms and the overall effect will likely depend on their relative magnitudes. Against this backdrop, the objective of this paper is to investigate whether the use of family labour is beneficial for farms in terms of its effect on production. The research question in this paper has been applied to agriculture. This is done because data for individual farms of necessary detail are easily accessible and there exists an interesting and topical policy debate. There are a number of other sectors of the economy where this question could similarly be considered. These include the construction industry, retail and a large range of services where small family owned and run businesses compete and coexist alongside larger corporate institutions. In all these cases, the potential effects of both the motivation and the management capability deterioration hypotheses could be important. However, in few other industries would we expect to find that the spatial dispersion of work activities plays such a role as in agriculture. Therefore, we could expect that the positive effect of family labour use would be more pronounced in farming. The study employs as a criterion for a family farm as the use of family labour in the broadest possible sense, i.e. any farm which employs family (unpaid) labour. The source of farm level data is the EU Farm Accountancy Data Network (FADN), since FADN allows the classification of farms according to the use of family or non-family (paid) labour. The investigation is detailed in respect of the farms' technical efficiency. The logic behind this is that in more efficient farms both family and non-family labour can be expected to have a higher output contribution. However, the incremental effect on the output might not be equal between the two types of labour. In order to estimate the incremental contribution of family labour to output, first, a non-parametric non-separable farm production function is estimated, and then estimates from it are used to compare the predicted output for a range of synthetically created family farms with the output from similar synthetic non-family farms. The measure itself is the estimated effect of family labour on total output, net of the output that would be generated if hired workers had been used instead. The result is reported per full-time equivalent family member engaged on the farm, measured in Annual Work Units (AWU). For this reason, we term this estimated effect of family labour as the average product of family membership (hereafter referred to as APfm). This measure allows the identification of the effect of family labour in family farms against a similar non-family farm benchmark-effect which can be either positive or negative. The above strategy is employed separately for four different EU Member States, each characterised by a different mix of family and non-family farms. These are the Czech Republic, Hungary, Romania and Spain. Since different levels of technical efficiency would invariably impact on the APfm, non-separable non-parametric quantile regression is used to estimate these effects for two different levels – 90 per cent and 10 per cent relative technical efficiency. These quantiles are chosen to provide realistic bounds for the investigation of how the effects under consideration vary across the spectrum of technical efficiency. The results of the empirical analysis provide a limited support for the claimed superior output effects of family farming and only then on more efficient farms. Where such effects exist, the estimates produced suggest that they are relatively modest and subject to a number of thresholds. The structure of the paper is as follows. The next section develops the theoretical framework and the model. Section 3 clarifies definitional issues and Section 4 details the empirical methodology. Section 5 presents the data and Section 6 discusses the results. Section 7 concludes. 2. Theoretical framework and model The theoretical framework developed here is general enough to capture both the motivational and the capability deterioration hypotheses. However, for simplicity, we illustrate its structure using only arguments of the motivational hypothesis. The framework is based on the assumption that transaction costs within the organisation of production activity are smaller when farm family labour is more extensively relied upon (Pollak, 1985; Allen and Lueck, 1998). This perspective assumes implicitly that all farms are efficient and considers their organisation as a set of incentives and mechanisms that achieve this efficiency. Therefore, in the analysis presented in this paper such considerations would only apply to the efficient farms and not to the inefficient ones. Furthermore, there is another subtle difference between the approach in this paper and this previous body of literature. While the transaction costs literature is interested in what mechanisms and incentives are better suited to achieve an optimal outcome, the question in this paper is ‘If these mechanisms and incentives vary, how would the outcome change?’ There is nevertheless a clear link between the transaction cost model prescriptions and this study. When the conditions, as defined by Allen and Lueck (1998), are conducive to family farming, the estimated APfm are expected to be positive and vice versa. In order to investigate the possible output effects of family labour the following stylised model is used. Let us assume an agricultural economy with n farms. The main term of interest is the output variable y. The latter is hypothesised to depend on two variables: e and s. From the transaction costs (corporate governance perspective), e could be viewed as a production (or organisational) incentive, while s would be the level of control that the owners can exercise over the outcomes of that incentive.2 The output relationship, i.e. the production function, which is a function of both of the production incentive and farm-specific level of control over it, can be denoted as follows: yi=fi(si,e),i=1,2,…,n (1) Note that the production incentive variable (e) is the same across farms, whilst the control one (s) varies. In other words, a common production technology is assumed, but different levels of control over it translate into different levels of efficiency. We do not, therefore, impose any structure on e, but do so on s. The response to the ‘control’ variable is an adjustment to an observed reference level of the output variable. In other words, each farm observes the reference level, i.e. the level of the output variable for the reference group the farm belongs to, or identifies itself with, and adjusts its efforts accordingly so that the farm output variable moves together with that of the reference group. Although formally this is an example of yardstick competition, such an assumption is compatible with a diffusion of management practices within a transaction cost model. For simplicity, it is further assumed that there is a single reference group, although this assumption is not essential and can be relaxed. The control variable can thus be quantified as the corresponding level (probably aspirational) of the output variable, relevant for the farm. In this way, the model is consistent with using a reference group for information processing, as well as a more general ‘identity’ kind of behaviour in which economic actors identify themselves with (or aspire to reach) a reference group. To keep the analysis general, specific mechanisms for the above effect are not assumed. If the quantified control variable s increases, the individual output variable y will also increase, even if the production incentive e does not change. This is because the farm tries to meet its perceived obligations (i.e. s). It is also reasonable to assume that when s increases, the corresponding increase in y is smaller. In the transaction cost perspective, this indicates that there are associated transaction and monitoring costs which reduce the net output. Therefore, for the purposes of the model, this implies that the partial derivative of f with regard to the control variable is less than one. A positive impact of economic incentives is also assumed. Hence, 0<fis<1,fie>0 (2) where the superscript refers to the partial derivative with regard to s and e variable, respectively. There is also another, quite important, technical implication of the above assumptions. They imply a decreasing marginal product of the control variable. This means that if one ignores it (or treats it as an efficiency level that modifies the technological production function, as we do later in this paper), it ensures that the production function interpretation still holds. The above also means a decreasing marginal ability to translate aspiration into outcome. Subject to the assumption of a single reference group, the control variable can be defined as si=1n−1∑j≠iyj (3) Hence, the control variable is the observed reference group level. It is then possible to restate this with multiple reference groups, i.e. as si=(1∑j≠imij∑j≠imijyj) (4) where for each i mij are membership indicators (i.e. mij takes the value of 1 if the jth farm belongs to the reference group of the ith farm and 0 otherwise). Again, if mij are fixed, meaning that farms are not allowed to shift between reference groups, the results would not change significantly. The process of changes in the output variable, informally described above, can be formally expressed as a system of differential equations as below: ṡi=μ(1n−1∑j≠ifi(sj,e)−si),i=1,2,…,n (5) In (5), the dot over s represents the time derivative, while μ>0 is the speed of adjustment. The question is whether model (5) has a stable equilibrium solution. Appendix A discusses the derivation of the equilibrium results following the arguments of Schlicht (1981). An important part of the derivation results relies upon the Lyapunov function approach for which interested reader could see Takayama (1985) (p. 349–380). Since in equilibrium yi=1n−1∑j≠ifj(sj,e), the impact of the production incentive e on the output variable can be calculated by differentiating the above expression (with regard to both s and e) which, after solving for the partial derivatives with regard to e, yields ∂y¯∂e=∑iaifie (6) with ai=1n(1n+fis−1)/(∑j1n+fjs−1−1)>1n (7) One may interpret ai as the coefficients of ‘structural homogeneity’. In a homogeneous agricultural economy they, ai, will all be close to 1/n. Actually, if the control variable is removed from all equations so far (assume that fis=0) the model reduces to a single representative farm model. Technically, the assumption that fis=0 would be equivalent to excluding the effect of any governance mechanism in the transaction cost perspective. When there are differences in the impact of control on output (i.e. in fsi), then a different structure emerges. Two borderline cases are considered below. Since 0<fis<1, these borderline cases are defined by fis→0 or fis→1 for all i. The former case gets close to the single representative farm model. The condition fis→0 means that the net output effects of the control mechanisms are negligibly small, probably because monitoring is ineffective, or the transaction costs associated with it offset its positive impact. On the other hand, with very effective control mechanisms (i.e. when all fis→1) ai will tend to infinity. It has to be noted that ai is strictly increasing if fjs increases for any j. This means that any increase in the importance of the control will bring about an enhancement in the effect of the production incentive. This enhancement may be viewed as an ‘efficiency step-change’ as the increased control effects enhance the ‘pure’ effect of technology. This is possible because the reference group definition of technology (i.e. that of the homogeneous agricultural economy) impacts to reduce the average efficiency effects. This ‘control multiplier’ can be calculated as c=∑iaifie1n∑ifie (8) Since ai>1n for all i, then c > 1. Equation (8) represents the direct increase in output, given a unitary ‘direct’ change due to technology. Another important observation concerns the speed of adjustment. Note that if all fis were equal to one (which is explicitly not allowed in our model specification), all eigenvalues of the Jacobian of the system of differential equations (5) would be zero, implying that the speed of adjustment in all directions is equal to zero. This means that a high level of control implies a rather slow speed of adjustment, while a lower level of control increases the speed of adjustment. Therefore, the rational choice of adopting a family or a non-family (corporate) structure for a farm also depends crucially on the planning horizons. Family farms are more conducive to longer planning horizons due to inter-generational transfers where the long-term effects of the control that the family organisation of production exercises over output are more valuable. When there are higher discount rates, i.e. when shorter term outcomes are of greater interest, non-family forms of farm organisation would be preferable since although the long-term outcomes might be inferior, the higher speed of adjustment means that they take less time to be achieved. In the analysis of a real-world production data, it cannot be assumed that the long-term equilibrium solution has been reached. This means that the above trade-off has also to be taken into account. Therefore, the Allen and Lueck (1998) conditions under which a family farm structure is preferable, and which rely upon the final equilibrium state and imply instantaneous adjustment, may need to be re-evaluated. In doing so, it is also important to consider the farm efficiency level. In general, for less efficient farms, the levels of the control variable are low, which leads to a lower equilibrium level, but also to a much higher speed of adjustment. In terms of output, it could be expected that for such farms, the speed of adjustment effects will dominate, meaning that APfm compared with the non-family benchmark will be negative. If, however, efficient farms with greater levels of the control variable are considered, then the reasoning is moving closer to the theoretical models that assume full efficiency, such as Allen and Lueck (1998) and Pollak (1985). Nevertheless, unlike these previous models, we consider the adjustment process, which means that we also need to take into consideration the stage at which the farms are in this process. Therefore, in addition to the conditions that Allen and Lueck (1998) defined and which lead to a higher output equilibrium solution, it is necessary to take into account the relative time that the farms have spent in adjusting towards such equilibrium outcomes. The general logic of the above argument is that when the conditions of Allen and Lueck (1998) are met, the long-term equilibrium output of family farms is higher than the one of non-family farms, but it takes longer to achieve it. Therefore, at the initial stages of adjustment, the higher speed of adjustment of non-family farms will make them more productive, while later in the adjustment process the family farms are expected to overtake them. Since the stage in the adjustment process is unobservable, it is necessary to find some type of indicator for it. The maturity of an agricultural sector, and in particular the family segment of the latter, might be a good proxy. Specifically, if one looks at a given country, sectors that meet the requirements of Allen and Lueck (1998) and have some longer tradition of specialisation would build competitive advantage which would signify that they are further on their adjustment path and, therefore, it is expected that family farming at this point of time would be more productive. Let us consider, for example, condition 4 of Allen and Lueck (1998) which states that under higher uncertainty family farming is preferable. Indeed, since the speed of adjustment under family farming will be lower, it will smooth the output path reducing variability. Concurrently, the ‘control multiplier’ will assume higher values leading to higher long-term equilibrium output. However, in the short term, this resilience to external shocks will reduce the ability to take advantage of favourable opportunities and when such shock or uncertainty persists, the short-term disadvantages will dominate, resulting in family farms experiencing negative APfm in comparison with non-family. Based on the arguments presented above, on the one hand, there are reasons to hypothesise that under certain circumstances family farms would be a superior form of organisation and would hence provide productivity gains over corporate farming. This is the main message based on the transaction cost approach. In this paper, this is termed a motivation hypothesis. Furthermore, since the study uses the amount of family labour employed as an indicator of how much a farm is rooted into the family tradition, we explicitly hypothesise that the motivational aspects will strengthen with a higher level of family orientation, i.e. in this case with a higher use of family labour. In other words, in its pure form the motivation hypothesis would lead to a positive APfm and this contribution is expected to increase with the use of family labour. On the other hand, there could be negative production effects due to the prevalence of social, as opposed to economic, considerations in family farming that could render corporate farm organisations superior. The type of effects dominant here is not, however, inconsistent with the transaction costs approach (see e.g. Pollak, 1985 who notes the possible multi-objective nature of family farms). There are different reasons why such social considerations can lead to suboptimal output outcomes. For example, non-economic objectives would distract the management from achieving purely economic outcomes, hence potentially reducing output. This latter type of effect is termed here as the management capabilities deterioration hypothesis. The main reason for using such a term is that from a corporate governance perspective a social type of motivation would result in reduced capability to achieve economic aims. Similar to the previous case, it can be further hypothesised that when a farm becomes more family oriented, the importance of such non-economic aims may increase, resulting in a larger negative effect on the output. Both these hypotheses are consistent with the theoretical model presented above. As mentioned previously, family farming would likely generate a greater level of control consistent with the motivation hypothesis, but also a lower speed of adjustment toward the steady state, which leads to a negative impact as hypothesised by the management capabilities deterioration hypothesis. Which one will dominate will depend on the trade-off between the steady state and the speed of adjustment. In a dynamic perspective, as adopted in the theoretical model, the motivation hypothesis associated with the steady state is more likely to hold in more mature sub-sectors, as a longer established sub-sector can be expected to have undergone most of the transition towards the steady state. Less mature sub-sectors, however, would likely be further away from the steady state and hence the speed of adjustment will dominate the determination of the effects, with the consequence that the lower speed of adjustment of family farms would lead to a negative APfm consistent with the management capabilities deterioration hypothesis. These effects are, however, unlikely to be present in such pure forms and the interplay between the two types of effects will determine whether the relative APfm is positive or negative. Finally, the relative magnitude of the production effects, irrespective of their pattern, would depend on the structure of the sector, with a higher degree of structural homogeneity (as expressed by ai in our theoretical model) leading to smaller effects. For example, whenever one form of farm structure dominates strongly in a country, this would imply a higher level of homogeneity and therefore smaller APfm would be expected. Linde (1982) offers an interesting static (steady state equilibrium) result for reference group models. In the terminology used in the present paper, Linde (1982) allows for heterogeneous response to the production incentive, but does not investigate the existence of equilibrium. As shown in Appendix A, the dynamics of such a model converges to a unique steady state. According to Linde (1982), overall optimality is achieved when units with high levels of production incentive apply high levels of control. This provides an interesting twist to the issue of family vs. non-family farms. Consider this with regard to the issue of technical efficiency. Since the latter is a product of the production incentive (more efficient farms will have higher values for the production incentive) and control (in that the higher levels of control lead to greater efficiency) this result means that these two components are correlated. In simple terms, this means that advantages of the ability to exercise control will most likely manifest themselves at higher levels of technical efficiency. Therefore, in terms of the assumption that family farming advantages can result from a higher degree of control, we should expect that this would be larger at higher levels of technical efficiency. Furthermore, the advantages of family farming are expected to increase with the additional level of control that they can achieve. Hereafter, we argue that the level of family involvement (that we measure by the use of family labour) can proxy such control. This means that we expect that increased levels of family involvement should increase the advantages of family farms. Hence, the implications of the theoretical models are as follows: advantages of family over corporate farming are likely to be dependent on the distance to steady state (which will be greater and hence such advantages smaller, if there was a recent economic shock), the level of structural homogeneity (generally unobservable, but can in some case be deduced from empirical results), the level of technical efficiency and the family involvement. In the empirical application, we explicitly account for the last two and the discussion of the results throws some light upon the other factors. 3. Definitional issues ‘Family farm’ and ‘family farmer’ may be defined in several ways. Definitions can be based on the absolute amount or the share of family labour used in the total labour input, on ownership and control (and thus succession between generations), on legal status (sole holders) or on who bears the business risk (Davidova and Thomson, 2014). During the debate in relation to the IYFF, FAO proposed that a family farm is an agricultural holding which is managed and operated by a household and where farm labour is largely supplied by that household (FAO, 2013). One important point in this definition is the emphasis on the operational aspect of the farm, i.e. the use of family labour. Several attempts have been made to define quantitative thresholds of the family labour in order to delineate the family farm sector. Matthews (2013) suggests that family farmers are those who are farming with labour input of up to 2 Annual Work Units (AWUs), since this may represent full-time employment of a farmer with spouse, or with daughter/son, or with one hired worker. Hill (1993) defines three groups of farms: first, family farms where the share of family labour, measured in AWUs, is at least 95 per cent of all full-time labour; second, intermediate farms with between 50 and 95 per cent of family labour; and, third, non-family farms where the holder and family members contribute less than 50 per cent of the labour. This study departs from the proportional (share) definition in light of the adopted theoretical framework. As already discussed, what makes a family farm is not the share of family to non-family labour, but the nature of the governance/monitoring mechanisms that the family involvement implies. Hence, from a governance perspective, what makes a farm a family farm is the fact that family labour is actively involved in mitigating monitoring problems and ensuring effective governance. In this sense, the involvement of family labour is better measured by its absolute quantity rather than its share. 4. Empirical methodology The empirical approach employs a non-parametric quantile regression. The quantile regression estimates the conditional distribution of the dependent variable with regard to a set of covariates. Since the conditional quantiles are, in general, different from the unconditional ones, it is necessary to highlight some points which are important for the interpretation of the estimates which follow. The particular interpretation depends on the nature of the conditional relationship that is being estimated. In this study, production functions are estimated. In this regard, upper conditional quantiles refer to farms which are able to extract more output from their given endowments, i.e. the inputs in the production function, than other comparable farms and vice versa. Hence, the conditional output distribution inferred from a production function measures the unobservable farm ability to transform inputs into output, thus it measures technical efficiency. The upper tail of this conditional distribution denotes more efficient farms while the lower tail refers to the least efficient ones. Here the unknown production function is estimated non-parametrically and thus avoids the necessity to specify any pre-defined functional form for production. The non-parametric quantile regression applied here can be expressed as y=fτ(X)+uτ (9) stqτ(uτ|X)=0. (10) In contrast to the more widely known linear quantile regression specification (e.g. Koenker, 2005), the effect of the covariates is given by a non-parametrically specified function, which itself is quantile dependent, and the conditional quantile restriction in equation (10) is specified with regard to this non-parametric function (see Li and Racine, 2007). There are two important consequences from the above. First, the effects of a particular input are given by a functional relationship, which will assign a set of values for such effects. Second, unless additivity of the effects of the production function is assumed, something that is clearly undesirable, then the implied non-additivity means that any effect will need to be calculated by, and conditioned on, some kind of averaging over the dataset. At this stage, in order to facilitate interpretation, it would be useful to contrast the quantile regression method to that of the more familiar mean regression. In mean regression the equivalent to equation (10) is something like u~N(0,σ2) (11) which is a combination of E(u)=0 and means that the functional relationship equation (9) being estimated applies to the conditional mean and some distributional assumption about the residuals. This would typically be a Gaussian distribution with a constant variance as in equation (11) above, although a variety of alternative distributional assumptions can be used instead. This has two important implications. First, the same relationship is essentially applicable to all observations in the sample and the residuals from it represent the conditional distribution y|X. This conditional distribution has an associated distributional assumption (usually Gaussian, as above, but alternative assumption could be used instead). In conditional quantile regression, the conditional quantile restriction in equation (10) specifies that the functional relationship (in equation (9)) refers to the respective conditional quantile. In other words we estimate a relationship that only applies at a given point of the conditional quantile distribution. Since we do not assume anything about the quantile residuals (derived from applying equation (9)), they do not have the interpretation of conditional distribution. However the quantile method allows one to estimate the whole conditional distribution of y given X. This could be done by estimating the quantile process, which technically means estimating as many quantile regressions as the number of observations in the sample. If one does this then effectively, a different functional relationship equation (9) will be estimated for each observation. There are various non-parametric extensions of the quantile regression model, using e.g. kernel approaches (Li, Liu and Zhu, 2007), inversion of non-parametrically estimated conditional density (Li and Racine, 2008), local estimation (Yu and Jones, 1998), smoothing splines (Koenker, Ng and Portnoy, 1994; Thompson et al., 2010), penalised variograms (Koenker and Mizera, 2003) and algorithmic approximation (Jiang, 2014).3 This paper adopts the approach of Takeuchi et al. (2006) who show that the optimisation problem of non-parametric quantile regression, when specified via regularisation based on reproducing kernel Hilbert spaces norm, bears resemblance to the approach widely used in the machine learning support vector regression. In fact, it is a simplified version of the ε-support vector machine regression problem. Technically, unlike the standard support vector regression, which requires pivoting, the estimates can be calculated by standard quadratic optimisation methods. This modelling approach is more amenable to the problem at hand since non-additivity is implicitly accounted for rather than being represented more explicitly in terms of higher order interaction surfaces as required in the kernel and spline approaches. This particular alternative has the important advantage of maintaining a lower computational workload and relative robustness with regard to the estimation of the (conditional) densities.4 Cementing our choice of modelling approach, this particular choice is that, once the corresponding models are estimated, predicting from them is much simpler than with most alternative methods. The paper employs Gaussian kernels to specify the reproducing kernel Hilbert spaces for the regularisation norm and a 5-fold cross-validation to select the optimal parameters. The latter is the main source of computational costs. The robustness of the results of this essentially novel application to an empirical problem is likely to be of particular concern to readers. We, therefore, felt that a multi-fold cross-validation was necessary in view of the computational complexity of the estimation problem and, thus, the additional computational costs were justified on these grounds. Two separate types of non-parametric quantile regressions were estimated at the 0.9th and the 1.0th quantiles. Since the former refers to farms which are more efficient than 90 per cent of the comparable farms and the latter refers to farms that are less efficient that 90 per cent of the other farms, hereinafter the two quantiles are simply referred to as ‘efficient’ and ‘inefficient’ farms. Intentionally, the analysis does not go too deep into the tails of the conditional distribution to eliminate the potential effect of outliers. As discussed in the theoretical model, we expect that the advantages of family farming will manifest themselves at higher levels of technical efficiency. Estimating via non-parametric quantile regression the whole quantile process would provide estimates for every farm in the sample. While theoretically and conceptually a 90 per cent technically efficient farm refers to a single farm in the estimation sample (for which the residual in equation (10) for τ=0.9 is zero), the non-parametric quantile regression provides point estimates for every single farm in the dataset, i.e. the unknown relationship fτ(X) is estimated over all farms. This means that the non-parametrically derived estimates for the relationship in equation (9) are derived at all points in the estimation sample. The interpretation of the result from this functional relationship shows what the output would be for every single farm if it had achieved that particular level of technical efficiency. In other words, although by fixing the conditional quantile we estimate a single point of the conditional distribution, the estimation then allows us to infer the production response of an efficient (or inefficient) farm as the mix of its inputs changes. Given the estimation this means that yˆ=fˆτ(X) gives us estimates of what the output of any given farm would have been if it had the pre-specified (e.g. 90 per cent) level of technically efficiency. Alternatively by applying the same to a different dataset or a farm's description in terms of mix of inputs, the same question could be answered. In a way, this is not that different from what efficient frontier models (which technically are 100 per cent quantile models) provide in that they allow one to specify what would be the optimal (i.e. maximum) output level for each farm. Here in contrast we can specify for any farm how its output would change with the level of technical efficiency (provided of course we estimate different quantile regression models for all such efficiency levels of interest). In this study, the interest is not on the overall production response, but on how it changes with regard to a particular input. If the additive model formulation was adopted, the overall production response could be split amongst the inputs (since in this case fτ(X)=∑j=1kfj,τ(Xj) for all inputs j=1,2,…,k). With a non-separable production function the above is no longer possible and any effects have to be conditioned with regard to a reference sample. In simple terms, this means that the production response of, for example, an efficient farm for any given mix of inputs could be estimated by a simple prediction from an estimated non-parametric (in this case 0.9th) quantile regression model. The effect of any particular input can therefore be obtained by creating an artificial prediction sample in which the values for this particular input are varied, but all other inputs are fixed at some ‘typical’ values. The resulting partial correlation effects will provide the ‘typical’ effects of the input of interest. Such a procedure would result in point estimates for the required effects while confidence intervals can be constructed by bootstrap (see Kostov, Patton and McErlean, 2008). A standard approach to defining what is ‘typical’ involves simply averaging all the other variables over the estimation sample and this approach is implemented in this paper.5 However, one has to be careful when averaging variables, particularly in non-separable models, since averaged combination of variables can still be atypical and a careful consideration should be given to both the feasibility and meaning of these combinations. In this study, the focus is on the effect of family labour. By standard averaging a synthetic reference farm that has the average stock of the other inputs is obtained. However, such an input mix might be unusual for a family farm. Economic efficiency arguments mean that only certain combinations of the other inputs would be conducive to using family labour. To correct for this, a second alternative approach is applied to create a reference. This involves averaging of the other inputs only over the family farms, i.e. the farms with non-zero family labour input. In this way, a ‘typical’ family farm is created. This might be more realistic since it studies the effect of family labour for an input mix that is feasible for family farms. In essence, the effects we calculate and present hereafter are counterfactual effects. They are counterfactual in that they are derived from the difference between their output and that which could be gained from otherwise identical family and non-family farms as appropriate. If such effects were to be directly estimated form the data the results would have been classified as quantile ‘treatment effects’ and issues of identification would have arisen. While identification results for additive treatment effects exist, to the best of our knowledge, no such results have been established for non-separable models. No such problems however exist in the counterfactual distributions analysis (see Chernozhukov, Fernández-Val and Melly, 2013 for additive models) which distinguishes type 1 counterfactual effects (effects based on changing the conditional distribution), type 2 (changing the covariate structure) and type 3 effects (which are based on changing both conditional distribution and covariate structure). The counterfactuals we use here are type 1 in the above terminology, and by their nature they require us to fix the covariate structure. The main difference is that dues to the non-separable nature of our model we do not construct the whole distribution of such effects, but instead focus on two distinct points of the conditional distribution, namely the ‘efficient’ and ‘inefficient’ farms. Conditioning on a reference sample allows us to calculate the output response to varying family labour input. The output difference between the reference sample and its non-family equivalent (i.e. a farm with the same inputs mix, but no family labour) is calculated. This difference, positive if the family farm output is larger than non-family, or negative in case the non-family equivalent has larger production, represents the total product of farm family membership (the TPfm). This incremental contribution is divided by the quantity of family labour to arrive at an estimate of the APfm expressed as per annual work unit (AWU) of family labour. Throughout the paper, we refer to the latter measure as the Average Product of Farm Family Membership (APfm). The way the reference (prediction) sample is constructed, allows estimating this APfm for varying degrees of use of family labour. Details on the derivation of APfm are presented in Appendix B. A bootstrap procedure is implemented to derive confidence intervals for APfm. Since this is a computationally expensive part we have implemented it as a part of the estimation process, i.e. have estimated all the bootstrapped models and saved them to use for prediction purposes in the APfm calculations. 5. Data The data used in the study have been derived from the EU’s Farm Accountancy Data Network (FADN), 2008. The FADN samples only holdings above a threshold, defined in terms of their economic size, so the very small (often semi-subsidence) family farms are excluded. The analysis focuses on four EU Member States which differ substantially according to their farm structure – the Czech Republic, Hungary, Romania and Spain. The Czech Republic has a particularly large corporate farm sector, which does not use family labour while Hungary presents an interesting mix between corporate and family farms. Romania is the EU Member State with the largest number of small family farms out of which 93 per cent are semi-subsistence, thus consuming more than half of their output within the household (Davidova et al., 2013). Semi-subsistence farms are not included in FADN but in reality they affect the nature of the commercial farms which are the FADN field of observation. Finally, Spain’s agriculture is dominated by family farms. Altogether, these four countries account for 12,929 observations in the EU FADN dataset, out of which 11,606 are family farms (89.7 per cent of all observations). There is a clear divide between the EU New Member States (NMS) and Spain. Although in all four case study countries family farms are predominant in the total number of farms, their share in total land cultivated by FADN sample farms and in total labour input in the Czech Republic, Hungary and Romania is much lower since they are each considerably smaller than their non-family counterparts (Table 1). Table 1. Sample data Czech Republic Hungary Romania Spain Number of observations 1344 1950 1351 8294 incl. family farms 874 1542 945 8245 Share of family farms (%) 65.0 79.1 69.9 99.4 Total labour (AWU) 23,096 11,414 12,413 14,956 incl. in family farms 2572 3147 2391 14,620 Share of family farms (%) 11.1 27.6 19.3 97.8 Total land area (UAA in ha) 730,079 415,821 368,846 428,596 incl. in family farms 128,392 141,074 34,882 422,039 Share of family farms (%) 17.6 33.9 9.5 98.5 Czech Republic Hungary Romania Spain Number of observations 1344 1950 1351 8294 incl. family farms 874 1542 945 8245 Share of family farms (%) 65.0 79.1 69.9 99.4 Total labour (AWU) 23,096 11,414 12,413 14,956 incl. in family farms 2572 3147 2391 14,620 Share of family farms (%) 11.1 27.6 19.3 97.8 Total land area (UAA in ha) 730,079 415,821 368,846 428,596 incl. in family farms 128,392 141,074 34,882 422,039 Share of family farms (%) 17.6 33.9 9.5 98.5 Source: Based on FADN, 2008. Table 1. Sample data Czech Republic Hungary Romania Spain Number of observations 1344 1950 1351 8294 incl. family farms 874 1542 945 8245 Share of family farms (%) 65.0 79.1 69.9 99.4 Total labour (AWU) 23,096 11,414 12,413 14,956 incl. in family farms 2572 3147 2391 14,620 Share of family farms (%) 11.1 27.6 19.3 97.8 Total land area (UAA in ha) 730,079 415,821 368,846 428,596 incl. in family farms 128,392 141,074 34,882 422,039 Share of family farms (%) 17.6 33.9 9.5 98.5 Czech Republic Hungary Romania Spain Number of observations 1344 1950 1351 8294 incl. family farms 874 1542 945 8245 Share of family farms (%) 65.0 79.1 69.9 99.4 Total labour (AWU) 23,096 11,414 12,413 14,956 incl. in family farms 2572 3147 2391 14,620 Share of family farms (%) 11.1 27.6 19.3 97.8 Total land area (UAA in ha) 730,079 415,821 368,846 428,596 incl. in family farms 128,392 141,074 34,882 422,039 Share of family farms (%) 17.6 33.9 9.5 98.5 Source: Based on FADN, 2008. In order to apply our methodology, the following variables have been extracted from the FADN dataset. The dependent variable is total output. The aggregate production function is specified with regard to labour, land (in hectares of utilised agricultural area (UAA)), capital and intermediate consumption. The total labour input is measured in AWU and is split into two variables: family labour and non-family labour. These two labour variables are used as separate inputs in the production functions allowing for differential effect of family and non-family labour. Capital is calculated as the difference between total fixed assets, on the one hand, and land, permanent crops and quotas, on the other hand. In this way a proxy for a long-term capital is obtained. The value of the land is excluded from the capital measure in order to avoid double counting since it is used as a separate input to the production function. FADN bundles together the value of land with permanent crops and policy quotas, and does not provide information for the quality of land. Finally, the total intermediate consumption is extracted as calculated in FADN. 6. Results As discussed in the methodology section, in order to present the effect of family labour in a non-separable production function framework, we need to invoke a ‘reference’ sample approach where all the other inputs are fixed at some ‘typical’ values. Here we apply two separate approaches to constructing such a reference sample, which we present separately. 6.1. Conventional reference sample In the conventional reference sample, all the other inputs are averaged over the whole data sample. The estimated APfm in the Czech Republic, Hungary, Romania and Spain are presented in Figure 1. Since very small values of family labour could signify occasional ad hoc use and may result in high variability of the estimated effects, only values of family labour of at least 0.5 AWU are used. Fig. 1. View largeDownload slide Estimated effects of family labour. (A) Contribution of family labour for the Czech Republic. (B) Contribution of family labour for Hungary. (C) Contribution of family labour for Romania. (D) Contribution of family labour for Spain. Fig. 1. View largeDownload slide Estimated effects of family labour. (A) Contribution of family labour for the Czech Republic. (B) Contribution of family labour for Hungary. (C) Contribution of family labour for Romania. (D) Contribution of family labour for Spain. The values of family labour in the synthetic reference sample, used for calculating the effects of interest, are a regular grid over the range of observed values in the data. However, these values are not uniformly distributed across the estimation sample. When the estimation sample only contains a few observations within a specific range, the estimated effects pertaining to this particular range should be treated with caution since they lack sufficient data support. For these reasons, the estimated effect is presented in rug plots, where rugs (vertical lines) are added to the horizontal axis to denote the empirical support for the corresponding estimates. The rugs are derived from the data used to estimate the effects, i.e. the rugs denote the corresponding observations in the estimation sample. In this case, they are plotted at the values for the horizontal axis, i.e. family labour. In this way, it is straightforward to visualise where there is relative scarcity of data. For example, in all graphs in Figure 1, there are limited number of observations above 3 AWU of family labour. There is, however, a difference from what our figures show and the standard practice. Conventionally, both the estimated effects and the rugs are derived from the same data (i.e. the estimation sample). Here the effects are calculated from a bootstrapped set of non-parametric quantile regression models, used to predict from the reference sample, while the rugs belong to the estimation dataset, i.e. they are based on essentially different (respectively prediction and estimation) datasets. Since the prediction phase uses estimated effects (which themselves are derived from the estimation dataset), the rug plots are essentially a visualisation device to ascertain the empirical support for these estimated effects and therefore could be interpreted accordingly. In the nutshell, the APfm is neither always statistically significant nor positive. The effect depends to a great extent on the level of farm efficiency. The differences in the effects on efficient and inefficient farms are quite large in most instances. Since, as it was argued previously, the level of efficiency can also be viewed as a measure of the managerial capabilities, these differences support the expectations that such management capabilities are crucial in determining the production effect of family labour. The results for inefficient farms confirm the predictions of the theoretical model and show a negative relative APfm. Two distinct shapes are observed for the efficient farms. The first one is a positive effect decreasing with the increase of family labour used and reaching a saturation level, as in the case of the Czech Republic and Romania. Such an effect is consistent with the motivation effect hypothesis. However, engaging family members in farming, beyond some threshold, may mean engaging lower skilled persons for non-economic reasons and this may offset or degrade the positive governance effects. It has been reported that often family farms retain surplus labour, while non-family farms are more flexible in their employment of unskilled workers. The second observed shape for efficient farms basically replicates the response shape observed in inefficient farms (see Hungary and Spain). This shape might best be described as a ‘dampened’ motivation hypothesis. A positive effect for the family labour emerges, but this effect flattens after a certain threshold of family labour input at about 2.8 and 3.6 AWU, respectively. The flattening of the effect may also be simply due to the nature of the data. Since family labour is subject to constraints in availability in absolute number terms, very large values may infrequent and, in cases, associated with data quality issues. On the background of these general results, some country differences provide interesting insights. In the Czech Republic, where most of the output is produced by corporate farms and only 11 per cent of the labour input can be accounted for by family farms (Table 1), the effect of family labour is positive, but relatively small for the efficient farms, while it is very large and negative for the inefficient farms. In the latter case, even when the use of family labour is increased, its effect still remains negative (Figure 1A). The small positive effect for efficient farms appears to be quite stable. This is consistent with the structural homogeneity argument, presented in the theoretical model, since the Czech Republic agriculture is dominated by corporate farms. For Hungary (Figure 1B), the effect of family labour for inefficient farms is significantly negative. The effect for efficient farms exhibits a downward slope at a low use of family labour, which reduces the positive effect making it insignificant, but at a threshold of around 1 AWU the slope reverses and the effect become significantly positive at approximately 1.75 AWU. After 2.6 AWU the effect flattens. This type of effect is likely produced by a combination of management capabilities deterioration hypothesis at lower levels of family labour use where the APfm is negative and downward sloping, and the motivation hypothesis at higher levels where this contribution is positive and generally increasing. There is also an intermediate range of interaction between the two (between 1 and 1.75 AWU) where the management deterioration hypothesis effects weaken and the motivation hypothesis effects start dominating. Referring to the theoretical model, this pattern can be derived from the interplay between the longer term equilibrium output, defined implicitly by the aspiration structure of the family farms, and the speed of adjustment to it. The speed of adjustment characterising family farms is lower which translates into negative effects in line with the management capabilities deterioration hypothesis. When family involvement increases, the control variable also increases, which creates the positive effects consistent with the motivation hypothesis. Romania (Figure 1C) is an interesting case. This is a country where agriculture is an important industry but has a strongly bipolar structure of holdings and there are very limited alternative employment opportunities for members of rural households. As such, we might expect that rural Romanian labour markets are less than mature and farms may find it possible to engage workers, especially family workers, in relatively unproductive tasks. The first striking feature of the estimated production effects of family labour are the very wide estimated confidence intervals. They suggest that farm heterogeneity may be a cause of serious concern in the case of Romania. Of course, data quality issues could also contribute to these results. Having said that, the qualitative picture suggested by the results appears fairly clear-cut. Family farm labour effects are statistically insignificant at a low level of family labour input, but always significantly positive (in spite of the very wide confidence intervals) for the efficient farms. In a way, this result can be viewed as a combination of the effects observed for the Czech Republic and Hungary. Bearing in mind that the share of family farms in Romania lies between this in Hungary and the Czech Republic (see Table 1), this could be expected. For Spain (Figure 1D), the effect of family labour use on efficient farms follows the same shape for both family and non-family farms consistent with the motivation hypothesis. Taking into account that there are only a handful observations above 4 AWU, the right part of the plotted effects (where they flatten out and decrease) for the efficient farms, can be ignored. For efficient farms, the effect becomes positive when family labour use exceeds 2.25 AWU and peaks at around 3 AWU. This threshold level is higher than in the case of Hungary, where a similar type of effect was observed. The effect is entirely negative for inefficient farms. 6.2. Family farms reference sample As already discussed, the above effects are calculated by a reference approach in which the other inputs are averaged across the whole sample. The second alternative approach is to average inputs only over the family farms. The family labour effects, estimated using this alternative ‘family farms only’ approach, are presented in Figure 2. Fig. 2. View largeDownload slide Estimated effects of family labour under family reference approach. (A) Contribution of family labour for the Czech Republic. (B) Contribution of family labour for Hungary. (C) Contribution of family labour for Romania. (D) Contribution of family labour for Spain. Fig. 2. View largeDownload slide Estimated effects of family labour under family reference approach. (A) Contribution of family labour for the Czech Republic. (B) Contribution of family labour for Hungary. (C) Contribution of family labour for Romania. (D) Contribution of family labour for Spain. In the case of the Czech Republic (Figure 2A), the effects for inefficient farms are by and large unchanged, however, the corresponding effects for the efficient farms look very different. Family labour no longer appears as an attractive proposition even for the most efficient farms. The threshold at which the effect for the efficient farms becomes positive is quite high (approximately 3.5 AWU) and although it is statistically significant, it is negligibly small. In an agriculture dominated by large corporate farms it is more difficult to discover positive effects for family farm labour and such effects only manifest themselves when the characteristics of these family farms approach those of the corporate farms, i.e. when they are large. For Hungary, efficient farms exhibit a negative effect, which, however, is only marginally significant, up to a threshold of approximately 1.25 AWU when it becomes insignificant. The second threshold is around 1.75 AWU when this effect not only becomes significant and positive, but increases considerably (Figure 2B). The largest production effect is observed at approximately 2.5 AWU of family labour input. This suggests that any positive effects of family labour are only manifested once almost two family members are fully employed on the farm. The dramatic increase in the effect around 2 AWU indicates that farms which are essentially family businesses are much more likely to be able to make efficient use of their family labour input. Beyond the peak in the family labour effect it starts decreasing and this decrease becomes significant beyond 3 AWU, consistent with the management capabilities deterioration hypothesis. However, since there are only a handful of observations within the range of above 3 AWU, which might be due to an outlier effect or a measurement error, the effects beyond 3 AWU should, therefore, be treated with caution. Furthermore, such a large use of family labour has a very limited practical applicability since few families have such labour endowments. The effect of family labour for inefficient farms is negative as suggested by the theoretical model. It only becomes statistically significant at around 3 AWU, but there are only a few data observations to support that range. Interestingly, the effects for efficient and inefficient farms are not distinguishable in terms of statistical significance within the range of up to 1.25 AWU. After this threshold, the effect for efficient farms not only becomes insignificant but also experiences an upward shift. The estimated effects for Romania (Figure 2C) change considerably in comparison with the reference approach in which the other inputs have been averaged across the whole sample. Both inefficient and efficient farms follow a similar upward slope pattern. The effects appear almost indistinguishable between the two levels of efficiency at a lower use of family labour (up to 1.5 AWU) and do not differ substantially up to 2 AWU. Furthermore, both these effects are insignificant. In comparison to the previous case when conditioning on the overall sample, conditioning only on family farms reduces considerably the confidence intervals. The remarkable coincidence of the estimated effects for differing levels of technical efficiency at a lower use of family labour may suggest that Romanian farms using low levels of family labour are predominantly inefficient. Efficient farms manage to achieve a positive effect at relatively high levels of family labour input. Although this needs to be interpreted with caution, there appears to be some empirical support in the observations which indicate a high family labour use. The results for Romania seem somewhat similar to those for Hungary, although there appears to be a more gradual transition as farms become more family involved. Yet the statistical insignificance of the APfm, except of the cases of a really heavy family involvement, is a result unique to Romania. It is possible that in addition to data issues and/or unobserved heterogeneity of farm structures, a characteristic difference from the other case study countries is the dualistic structure of Romanian agriculture with its small number of large farms and large number of small semi-subsistence farms. Although the latter are outside the scope of FADN, the important difference in Romania might be between the semi-subsistence and the commercial sector leading, to a relative homogeneity of the latter and disguising the differences between family and corporate farms within the commercial agriculture. For Spain (see Figure 2D), the family farm only alternative does not affect the results and they are virtually indistinguishable from those presented in Figure 1D. Therefore, the estimated effects of family labour do not depend on the type of conditioning used in constructing the reference sample. This is to be expected since most of the Spanish farms are family farms, so reconditioning changes little with regard to the reference sample. 7. Conclusions and policy implications It is often claimed that family farming is a ‘superior’ form of organisation of agricultural production compared to the non-family ‘corporate’ farming. The theoretical arguments related to the superiority of family farming are centred around family labour which could be more productive and requiring of lower monitoring costs as it is more motivated in its role as a residual claimant on farm profits (Pollak, 1985; Allen and Lueck, 1998). However, using a dynamic model, two distinct hypotheses about the nature of such effects are identified in this study; the motivation hypothesis, which is aligned with the transaction costs perspective, and the management capabilities deterioration hypothesis. The empirical results reproduced here reveal a pattern that is consistent with the interplay of these two hypotheses. While the overall pattern is of an increasing average product of farm family labour use for efficient farms, two specific thresholds indicate the existence and importance of the management capabilities deterioration effect. The first is that for low values of family labour use where the aggregate effects are negative, denoting that the negative, management capabilities deterioration effect, is of greater magnitude than the positive motivation effect, since the benefits of better governance are low at a low level of family labour input. The other indicates a flattening of the response in average product of farm family labour use at a relatively high threshold, which could be explained by an offset of the positive effect by engagement of more family labour for social and non-economic purposes. Overall, the shape of the estimated average product of farm family membership, which becomes positive over some range of family labour input for efficient farms, appears to support the motivation hypothesis. However, the magnitude of these effects is decreasing with the increase in the relative homogeneity of farm structures, exemplified by e.g. the results for the Czech Republic. Furthermore the width of the estimated confidence intervals varies considerably with Spain and the Czech Republic producing narrow confidence intervals and Romania yielding very wide confidence intervals. It is possible that some of the above could be due to the quality of the data, but the inherent heterogeneity of the farm structures in Romania may contribute significantly to such an effect. Reconditioning the reference approach in which the non-labour inputs are averaged across the overall estimation sample to the alternative of averaging the non-labour inputs only over the family farms alters dramatically the results for the EU NMS but appears to leave the results for Spain unchanged. The estimation results indicate that the average product of farm family membership on inefficient farms is either negative or statistically insignificant. Therefore, the family form of farm organisation appears unable to overcome the disadvantages of technical inefficiency. Increasing family labour input appears to further decrease the productivity of inefficient farms, or in the best case, to keep it at the same low level. Maintaining inefficient family farms in business through the EU CAP support, in particular Pillar 1, can hardly have economic justification in light of these results. This support helps to bolster farms that fulfil mainly social functions, such as the preservation of family values, act as a buffer to rural unemployment in poorer rural regions and slow down rural–urban migration. CAP Pillar 2 rural development measures in contrast may be more usefully targeted to support family farming. Potentially useful interventions from Pillar 2 could include the facilitation of inter-generational transfers, the promotion of structural change through retirement schemes, improving farm efficiency and competitiveness via investments in farm modernisation, and improving the environmental performance of family farms (Hennessy, 2014). Support to producer groups may also offset the negligible market power of individual family farmers and facilitate their integration into the modern food chain may also be of value although this goes beyond the scope of the work reported here. All these measures could potentially boost the efficiency of family farms and help to increase the average product of farm family members and to promote a more sustainable, less policy dependent, future for the family farm as an entity capable of producing both economic and social benefits. Or results suggest that a claim that family farms are superior to other forms of organisation in agriculture can only be made under certain caveats and then only for farms which are relatively more technically efficient. To use the claim as a simple generalisation, as it so often is, is likely flawed in most cases. Supplementary data Supplementary data are available at European Review of Agricultural Economics online. Footnotes 1 In this work, we will use the term corporate farms to refer to all types of farm business which are not wholly or majority controlled by the family of the manager. As such, these farms will include farming companies and production cooperatives. 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Google Scholar CrossRef Search ADS Appendix A The system of differential equations needs to be investigated for an equilibrium solution ṡi=μi(1n−1∑j≠ifj(sj,e)−si),i=1,2,…,n (A1) There are two different steps in this: existence and uniqueness. The uniqueness depends on considerations of convexity (see Schlicht, 1981) and is established by the fact that the Jacobian of the system of differential equations above has a dominant diagonal (i.e. is a diagonally dominant matrix). In the case with multiple reference groups si=1∑j≠imij∑j≠imijfj(sj,e) (A2) the corresponding systems of differential equations., i.e. ṡi=μi(1∑j≠imij∑j≠imijfj(sj,e)−si),i=1,2,…,n. (A3) First let us consider the equation (A1). The Jacobian of this system of differential equation has diagonal elements of −μi while the off-diagonal elements are of the form μi1n−1fjs for ∀j≠i. The sum of the off-diagonal elements for the ith row is then is μi1n−1∑j≠ifjs Then since fjs<1 (see the assumptions) it follows that μi1n−1∑j≠ifjs<μi and since μi=|−μi| this proves the dominant diagonal. For equation (A3), the sum of the off-diagonal elements on row i is μi∑j≠imij∑j≠imijfjs<μi∑j≠imij∑j≠imij=μi∑j≠imij∑j≠imij=μi=|−μi| Therefore, we have a dominant diagonal. So to summarise, the equilibrium solution is guaranteed to be unique irrespective of whether individual farms react to single or multiple reference levels. As for the existence, it can be established by the stability conditions of the Lyapunov function method. In this particular instance, we need to consider the following Lyapunov function L=maxi|ṡi|=maxi |μi(1n−1∑j≠ifj(sj,e)−si)i |=maxi|Ai|. Let us denote by θ the index that maximises the above expression over the next time period. This means that L=|Aθ|. With this in mind taking derivatives with regard to time will yield (dot over function denoting as in the main text time derivatives), we obtain L̇=Ȧθsgn(Aθ) Then Ȧθ=μθ (1n−1∑j≠θfjsAj−Aθ ) where fjs denotes the derivative of fj with regard to s. Now since |Aθ|≥|Aj| (by definition) and fjs<1 (by assumption) for ∀j 1n−1∑j≠θfjsAj−Aθ≤1n−1∑j≠θAj−Aθ therefore Ȧθ and Aθ will have different signs. Then whenever the derivative L̇ is defined, since L̇=Ȧθsgn(Aθ) clearly L̇<0. Therefore, taking into account that L is continuous and differentiable function, the fact that its differential with regard to time is negative means that it is decreasing over time. The latter shows that the system of differential equations has a stable equilibrium solution. It can be shown alongside the same line of reasoning that the above holds under multiple reference groups formulation. Appendix B Estimation of APfm: implementation details As noted in Koenker and Bassett (1978), the quantiles can be alternatively defined as the solution to an optimisation problem, namely minμτ∈ℝ (∑i=1nρτ(yi−μτ) ) (B1) where ρτ(.) is the so-called check function (also referred to as a pinball loss function) ρτ(u)=u(τ−I(u<0)) with I(.) being the indicator operator. By replacing the scalar μτ in equation (B1) above with a known parametric function μτ(X,β) the unconditional quantile is generalised to obtain conditional (on a set of covariates X) quantiles. These regression quantiles are formally expressed as minβ∈ℝ (∑i=1nρτ(yi−μτ(X,β)) ) (B2) When μτ(.) is a linear function, equation (B2) represents the optimisation problem that yields the solution to the linear quantile regression. Any other parametric function can be used to define a parametric (nonlinear) quantile regression. It would then be straightforward to generalise this to unknown function f(.) min (∑i=1nρτ(yi−f(X)) ). (B3) However, equation (B3) is no longer a valid optimisation problem since we need to also estimate f(.) and this entails making some additional assumptions about its nature. Estimating f(X) in this non-parametric setup can proceed in two ways. The first is to adopt an approximation to the unknown function (e.g. splines, series expansions, kernel, etc.) and basically treat this approximation as a known parametric function as in equation (B2). The other approach, which we follow here, is to explicitly define such an approximation as a representation of the density function of the dependent variable with regard to and the covariates. Since the latter implicitly depends on the unobservable joint probability function (and we only observe y and X), regularised version of the empirical risk function can be employed to recover an estimate of the unknown function. More specifically, we minimise the following empirical risk function: R(f)=1n∑i=1nρτ(yi−f(X))+λ2‖g‖2 (B4) where ‖.‖ is the RKHS (reproducing kernel Hilbert space) norm and g is the part of f that is being regularised. Since deriving valid quantile estimates require unpenalised offset term, g above is just the difference between f and the offset term. Here the estimation explicitly relies upon the dual to the above optimisation (see Takeuchi et al., 2006 for details). The unknown function is approximated by kernel approach. The reported results use Gaussian kernel. This requires optimal bandwidth to be calculated. The latter is obtained via 5-fold cross-validation. In order to explain the marginal incremental effect of family labour, let us introduce some additional notation. The estimated τ quantile regression can be represented as y=fˆ(X)+ξ (B5) with yˆ=fˆ(X) being the fitted values from the estimated model. We can view fˆ(X) as a predictor function and use it to predict the output for any set of inputs. To derive the incremental effect of family labour we create two artificial ‘samples’, Xfam and Xnonfam. These are identical with regard to all inputs except labour. Xnonfam does not contain any family labour input, while Xfam has non-zero values for family labour varying on a range replicating the range of values observed in the estimation sample. The other inputs are fixed at typical values, as defined in the paper. The total incremental effect of family labour, the total product of family membership net of that expected from the use of otherwise equivalent hired labour (TPfm), is calculated simply as the difference in predictions between the family and non-family synthetic samples as follows: TPfm=yˆfam−yˆnonfam=fˆ(Xfam)−fˆ(Xnonfam). (B6) The average product of farm family membership (APfm) is then obtained by dividing the above by the units of family labour used, i.e. APfm=TPfm/(familylabour). (B7) Hence, if we use an estimated quantile model to produce predictions f^(.)APfm can be easily calculated from equations (B6) and (B7). In order to produce confidence intervals we essentially bootstrap equation (B7) via subsample bootstrap. In practical terms this means the following: Create a subsample of the original data by randomly subsampling a portion of 70 per cent of the original data. Estimate the corresponding quantile (0.1 and 0.9) regression model for each of the subsamples. Calculate the APfm for each subsample, by using the predicted values corresponding quantile model and the two reference samples. Use the (empirical) sampling distribution of the APfm to calculate confidence intervals. In practical terms, steps 1 and 2 and independent of the creation of family and non-family reference samples needed for step 3. Since this is a computationally expensive part, we have implemented it as a part of the estimation process, i.e. have estimated all the bootstrapped models and saved them to use for prediction purposes in the APfm calculations. Author notes Review coordinated by Giannis Karagiannis © 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: ** Mar 15, 2018

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