Abstract
The empirical analysis of inequality of opportunity centres on disparities between social types, defined by the exposure to circumstances beyond individual control. Despite this, its main theoretical foundation—the Roemer model—does not indicate how to carry out, in practice, the required partition of the population into such types. This paper operationalises this definition of social types using a latent classes approach. Our specification is embedded in a probabilistic extension of the canonical Roemer model, which assumes that the relevant population consists of a finite number of latent types, from which each individual can be treated as a random draw. This makes possible the use of the full set of circumstances in the data, allows for unobserved individual heterogeneity and does not require an ex-ante specification of the number of types by the researcher. Our approach is illustrated by an empirical application featuring a large UK cohort study that was used in earlier literature to examine inequalities of opportunity in a wide array of social outcomes.
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Notes
This problem is clearly alleviated in cases where the researcher is solely interested in a particular type of inequality, such as gender or racial disparities. Yet, even in these special cases, empirical analyses often suggest that more complex stratifications are needed, involving a wider set of circumstances than gender and ethnicity (see, for example, Johnson 2010 on the characterization of racial segregation in the US).
Ad hoc solutions are particularly hard to defend in the context of ex-ante analyses of inequality of opportunity, since these centre on the measurement of inequality between social types (the term ex-ante refers to the fact that this approach can be used in cases where circumstances are known, but effort has not been exerted by the individuals—see Fleurbaey 2008 for details).
Although our approach does not entirely eliminate arbitrariness in the definition of types that characterizes earlier work in this field (this is inherent to the operationalization of the responsibility cut, distinguishing between circumstances and effort), it reduces it in three major ways. First, by allowing the researcher to use a much richer set of information, eliminating the need to, more or less arbitrarily, omit certain circumstances. Second, by taking into account unobserved heterogeneity in circumstances. Third, by providing applied researchers with a well-established statistical method for treating the information circumstances. This is far less arbitrary than the ad hoc selection of a small number of circumstances in the data.
Note that the level of effort depends on the whole policy (see Roemer 2003).
The use of rank \(\pi \) as an interpersonally comparable measure of effort is precisely justified in Roemer (2003).
It should be noted that the van de Gaer and Roemer approaches are equivalent in cases I which there is a type dominated by all other types for each degree of effort.
TIP curve originated in the poverty literature (see Jenkins and Lambert 1997) and has more recently been applied to the analysis of economic inequality, including inequality of opportunity.
He also proposed to minimize the maximum inequality throughout the different levels of relative effort and the inequality between the average outcome of each type of individuals.
In general, these complete orderings allow decomposing total inequality into inequality of opportunity and inequality of effort components, as shown by Ruiz-Castillo (2003), Checchi and Peragine (2010) and Ferreira and Gignoux (2011). Using an ex-ante criterion, the population is partitioned according to individuals’ circumstances and inequality of opportunity is evaluated in terms of differences between individuals endowed with the same circumstances (the between-group component of overall inequality). Adopting an ex-post approach, the population is firstly partitioned into types, according to individuals’ circumstances, and then each type is further subdivided according to personal effort. Correspondingly, inequality of opportunity is measured betwen individuals who have exerted the same effort (the within-group component of overall inequality).
If \(C=1\) all individuals share exposure to the same set of observed circumstances; If \(C=\hbox {N}\), it is not possible to find two individuals in society with the same set of observed circumstances.
Note that the canonical model implicitly assumes that the sets \(t\) and \(c\) coincide, and therefore, all probabilities collapse to either zero or one and \(v_i^t (\phi )=v_i^c (\phi )\) for \(t=c = 1,\ldots ,T\).
It should however be noted that the latent classes approach is an effective method for defining social types irrespective of the particular characteristics of this probabilistic extension of the Roemer model. It is fully compatible with it, but the use of latent class models would be entirely justified on the basis of its practical expediency, as made clear in Sect. 1.
Note that if \(\left\{ {C_1 ,\ldots ,C_K } \right\} \) are all binary, then system consisting of Eqs. (12) and (13) constitutes a well-known special case known in the literature as a Rasch model (see Rasch 1961). Also it should be noted that, in our model, type membership does not depend on the distribution of the outcome of interest, although this feature could be easily incorporated in a latent class specification, as shown in Cameron and Trivedi (2005, pp. 622–25). That kind of specification, in which class membership depends on the outcome of interest, has been widely used in the health economics literature, for example to model healthcare utilisation in the presence of unobserved heterogeneity. Bago d’Uva (2006) uses latent class models to estimate, simultaneously, healthcare utilisation (the outcome of interest) and class membership probabilities. For simplicity we do this in our empirical illustration and thus refer the reader to Cameron and Trivedi (2005) and references therein.
Alternative classification rules have been suggested for cases in which, for a substantial share of the sample, the highest and the second highest posterior probabilities of type membership are particularly close; an in-depth discussion of these can be found in Vermunt and Magidson (2004).
These small area data are available under a special licence, which imposes restrictions on the handling and usage of the data. Details can be found at http://www.cls.ioe.ac.uk/studies.asp?section=0001000200030015.
The childhood morbidity index is the sum of points, where one point is attributed to the occurrence of each of the following medical conditions: infectious diseases; ear and throat problems; recurrent acute illnesses; acute illnesses (other); asthma, bronchitis and wheezing; allergies; chronic diseases (medical); chronic physical or mental handicaps; chronic sensory illnesses; injuries; psychosocial problems; psychosomatic problems; other childhood morbidity (unspecified).
Most variables in the local area data used to characterize the socioeconomic milieu of the cohort-members (e.g., percentage of unemployed, social housing tenants, and skilled–unskilled workers) are continuous, negative skewed and feature a large number of zeroes. In practice this leads to a very large number of empty cells, causing numerical problems in the computation of the variance-covariance matrix, thereby making estimates inefficient and reducing the power of statistical significance and goodness of fit tests. We dichotomize these variables as shown in the table; as a robustness check we also estimated the model using a series of different partitions (such as terciles and quartiles) and the results are not affected. This robustness analysis is shown in the working paper version of this article, available at http://www.jgabriel.net/page3.htm.
\(BIC\left( \hat{\psi } \right) =-2L\left( \hat{\psi } \right) +\log \left( n \right) \upsilon \).
The details of these analyses are available in the working paper version of this article, downloadable from http://www.jgabriel.net/page3.htm.
These are shown on the last row of Table 8. Armed with these probabilities, and denoting the required shares by \(X_t \), these are obtained from the system of equations: \(\left\{ {{\begin{array}{l} {{\begin{array}{l} {\log \left( {X_2 /X_1 } \right) =-0.974} \\ {\log \left( {X_3 /X_2 } \right) =0.485} \\ {\log \left( {X_4 /X_3 } \right) =-0.0531} \\ \end{array} }} \\ {\log \left( {X_5 /X_4 } \right) =-0.462} \\ {X_1 +X_2 +X_3 +X_4 +X_5 =1} \\ \end{array} }} \right. \).
For clarity, we have restricted the number and categories of circumstance variables shown in Table 3. The full table of estimates of posterior probabilities is available from the authors.
In addition, Stevenson and Wolfers (2008) suggest that the measurement of inequality in life satisfaction is particularly sensitive to how narrowly social groups are defined in practice. This provides an additional (empirical) motivation for examining the definition of social types in context of life satisfaction.
It should be acknowledged, however, that the issue of reporting heterogeneity in life satisfaction remains controversial. Nonetheless, as mentioned above, our goal is to illustrate the latent classes approach, not to develop a full-fledged empirical analysis to clarify this controversy. We thus assume, for simplicity, that there is no reporting bias in life satisfaction, thereby treating this variable as a measurable quantity. This simplifying assumption is also convenient to make our example consistent with most of the applied work on the Roemer model, which focuses on more objectively measurable outcomes, such as education, health or income.
The results of these tests are available upon request from the authors.
The advantages of LCMs are methodological and explained above; they do not depend on the identification of stochastic dominance relationships in any particular example, such as this empirical illustration.
This example covers the case where the two approaches lead to a different number of types (three in the ad hoc definition and five in the latent classes one), since this is the most frequent in empirical applications. Although an artificial example comparing the same number of types under the two approaches could be constructed, this would be incongruous: one of the main advantages of the LCM approach is to provide the researcher with the number of types (rather than this having to be defined ex-ante); using a number of types that is different from our best model would thus be incoherent.
These models have been widely used also in the happiness literature.
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Acknowledgments
We are grateful for comments on earlier versions of this work from John Roemer, Dirk van de gaer, Valentino Dardanoni, Juan Prieto-Rodríguez, Rafael Salas and seminar participants at the University of Oxford. The NCDS database was supplied by the Economic and Social Research Council (ESRC) Data Archive.
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Li Donni, P., Rodríguez, J.G. & Rosa Dias, P. Empirical definition of social types in the analysis of inequality of opportunity: a latent classes approach. Soc Choice Welf 44, 673–701 (2015). https://doi.org/10.1007/s00355-014-0851-6
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DOI: https://doi.org/10.1007/s00355-014-0851-6