Abstract
The nexus between income and happiness is very much disputed. Many cross-sectional studies seem to be in support of a positive relationship. Yet, the failure of most studies to find a similar link between increases in income through time and happiness in developed countries of the western hemisphere sparked an intense debate over the issue. Starting from the fact that the theoretical basis in happiness research has been comparatively weak, we develop a novel theoretical approach that allows us to identify distributional consequences of unemployment as a key factor in the nexus. Social cleavages rooted therein imply a bias in the social choice between private and public goods with the bias and thus the importance for happiness conditional on the level of per-capita income. Our theory is backed by corresponding empirical evidence in international data: controlling for a number of variables, we find that, in low-income countries, subjective well-being significantly depends on income per capita; however, in high-income countries, the unemployment-related distribution is more important as a determinant, with significance shifting from the level of per-capita income to cleavages associated with unemployment. Our findings thus emphasizes the relevance of the income-satiation hypothesis found in many longitudinal studies also in cross-sectional perspective.
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Notes
Our focus on fundamental differences is inter alia inspired by casual evidence from international happiness data that merits explanation. According to 2000/01 data of the World Value Survey and the World Bank’s Development Indicators, Indonesia and Finland, for instance, attain comparable happiness indices, although per-capita income in Finland was almost tenfold. It also seems more than just an illustrating fact that Finland ranks top in suicide statistics (Cameron 2005, 203–206) but is a comparatively rich country and obviously does not fit into the results by Di Tella et al. (2003, 812) finding “that higher levels of national reported well-being are associated with lower national suicide rates”.
Our cleavage concept is an import from political science and goes back to Lipset and Rokkan (1967). They identified a number of developments in the aftermath of the industrial revolution, which, according to them, constitute cleavages, such as, for instance, state/church, owner/worker and urban/rural. In contemporary political science, having work or not is seen as a modern cleavage of western civilization.
See, e.g., Easterlin (1974, 2005). Easterlin (2009) himself summarizes his main findings as “ […] the seeming contradiction between the cross-section evidence…and the time-series evidence. The cross-section evidence is that happiness and income are positively related. That’s true on comparisons at a point in time among income groups within a country. It’s also true of comparisons at a point in time of richer and poorer countries. The paradox is when you look at what happens within a country over time, as income goes up, happiness does not rise the way one would expect it to, on the…[cross-section basis]”. The Easterlin paradox also ties in with the well established fact that a lottery millionaire is not necessarily better off in terms of happiness than before. See the seminal work by Brickman et al. (1978). Recent longitudinal studies by Gardner and Oswald (2007) or Apouey and Clark (2013) show more diverse effects, however, their focus is more specifically on physical and mental health.
Recall the general formula for the Gini-coefficient \(G=1+\frac{1}{n}-\frac{2}{n^{2}\bar{e}}( e_{1}+\cdots +me_{m}+\left(m+1\right)e_{m+1}+ \cdots +ne_{n})\) with \(\bar{e}\) average earnings and \(e_{1}>\cdots >e_{m}>e_{m+1}>\cdots >e_{n}\). With individuals \(\left(m+1\right)\) to n earning no income at all and other earnings equal, the expression shortens to \(G=1+\frac{1}{n}-\frac{2}{nm}\left(1+\ldots +m \right)\). Substitution of the sum of the arithmetic series \(s_{m}\mathrel{\mathop:}=1+\ldots +m=\frac{m}{2}\left(1+m \right)\) then yields \(G=\left(n-m\right)/n\). Naturally, in case of m = n, G will be zero.
With \(U_{S}/n=\left(1-G \right)\left(\left(\alpha -0.5\beta e\right)e+0.5\left(\left(n-1 \right)\alpha +\beta e \right)^{2}/\left(\left(1+n^{2}(1-G) \right)\beta\right)\right)\).
Naturally, the satiation point with respect to income shifts if parameters other than the Gini are subject to change. If so, happiness does not necessarily peak when tracking empirically.
Since we separated the decision on the expenditure side from the revenue side à la Musgrave and Musgrave (1989) when determining supply and demand for the public good, individual earnings e must not be too small as otherwise the public good cannot be financed. Therefore, we impose Y > X G which requires \(e>\alpha\left(n-1 \right)/\left(\beta n^{2}\left(1-G \right)\right)\). With the lower bound on e, the result of utility being positive despite e = 0 turns out to be purely virtual. In addition, we impose an upper bound with e < 2α/β in order to ensure that utility from the consumption of private goods is positive, i.e. \(U_{i}\left(x_{p} \right)>0\), for all n including \(n\rightarrow \infty\). In Fig. 1 we therefore confine numerical values of e to the economically relevant range 0.905 < e < 19.05, given the numerical values of α, β and n.
Points 1 and 2 might describe the situation in the two parts of Germany prior to 1990: in West-Germany, income was on average clearly higher, but accompanied by remarkable and steadily increasing unemployment; in East-Germany, by contrast, income was by far lower, but fairly evenly distributed, with high “employment”. It thus seems not only pure nostalgia that some East-Germans still remember their life during the times of the German Democratic Republic as considerably happier than in the re-united Germany—not least because in this society of “equals” (except for the nomenklatura) people stood together and built some sort of social capital in their opposition vis-à-vis the communist government that got lost after reunification. On empirical evidence with respect to happiness in the transition see Guriev and Zhuravskaya (2009) or Easterlin and Plagnol (2008).
Moreover, the “happiness-peak” in the left hand panel increases in G, i.e. the higher unemployment, the higher must be earnings: \((\partial e/\partial G)\mid_{U=U_{max}}=\alpha/(\beta n^2(1-G)^2)>0\).
The data and the complete analysis of S&W (2008) can be downloaded from the authors’ homepage (http://users.nber.org/~jwolfers/data.php# EasterlinData; last access June 1, 2013) and thus can be reconstructed quite easily.
Detailed information on the World Values Survey can be obtained from the World Values Survey Association (http://www.worldvaluessurvey.org). The World Development Indicators are provided by the World Bank (http://www.worldbank.org/data). The Penn World Tables can be downloaded at https://pwt.sas.upenn.edu. The OECD’s Labor Force Statistics can be obtained from the OECD (http://www.oecd.org). Links as of June 01, 2013.
For similar control variables (e.g. religion, political ideology, tolerance of outgroups, level of democracy, free choice, or private relationships) that performed well see Inglehart et al. (2008) or Vanassche et al. (2013). On the importance of “social capital” see, for instance, Helliwell and Putnam (2005) or Caunt et al. (2013). An interesting discussion on the use of different indices to proxy well-being can be found in Wolff and Zacharias (2009). Van Praag and Ferrer-i-Carbonell (2004) examine the determinants of happiness theoretically as well as empirically, focusing inter alia on measurement issues.
Overall, individual happiness information from the World Value Survey is obtained for 171,869 individuals from 83 different countries. When including individual and macroeconomic control variables (except the unemployment rate), data is restricted to 31,240 individuals living in 30 countries. When further including the labor force statistics of the OECD, the sample ends up with 22,676 individuals living in 20 countries.
From a methodological point of view, regressing ordered individual information simultaneously on individual as well as aggregate information is by no means conventional. Thus, we implement an estimation procedure based on Chamberlain (1980) as well as Ferrer-i-Carbonell and Frijters (2004). This estimation procedure takes account of possible endogeneity problems between happiness and the exogenous variables of interest. Since individual information is explained by aggregated variables, contemporaneous correlation can not be assumed to bias estimation results.
The World Bank country classification, which draws on the World Bank Atlas method (http://data.worldbank.com/about/country-classifications), suggests different income levels to distinguish between countries in empirical analyses: 1,005 US-$ or less for low-income economies, 1,006 US-$ - 12,275 US-$ for middle-income economies, and 12,276 US-$ and more for high-income economies. In this contribution, however, we are not able to apply this typical three-type classification. The inclusion of the countries’ unemployment rate constrains our data to OECD countries (that are middle or high-income economies) only. Regarding the specific literature on happiness research, Inglehart and Klingemann (2000) as well as Layard (2003) suggest a threshold level of 15,000 US-$ GDP per capita. However, sticking to one specific threshold-level is not indisputable. We therefore present estimation results for three different kinds of threshold-levels: 15,000, 20,000, and 25,000 US-$ in GDP per capita.
Additional robustness checks (not presented in the Table) show that our results also hold when replacing the exogenous variable log GDP with the real values of GDP per-capita. While average income is increasing individual happiness statistically significant in low-income economies, it is not significant in countries with higher levels of income. Instead, it is inequality as indicated by the unemployment rate that significantly impacts individual happiness, provided incomes are sufficiently high. Also when using pure metric information in case of exogenous variables (that is replacing the ordered information of individual income and the education level with a range of dummy variables: ten dummies for the information on income and three for the level of education), what is necessary for precise estimates from a theoretical statistical point of view, our findings on the interplay between aggregate income and inequality are robust and thus substantiated.
Naturally, two caveats concerning data and sampling still remain with respect to results. First, although the data set contains observations from more than 20,000 individuals, it still is a sample. Other data sets or different subsamples may support, validate, or even conflict with our findings. This caveat is especially important as for various reasons (labor-market issues, data availability etc.) the sample refers to OECD countries. Second, even when cross-country differences are partly captured by aggregated exogenous variables, heterogeneity in individual responses to the happiness question may bias results. However, both of these issues pertain to empirical happiness research in general.
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Dluhosch, B., Horgos, D. & Zimmermann, K.W. Social Choice and Social Unemployment-Income Cleavages: New Insights from Happiness Research. J Happiness Stud 15, 1513–1537 (2014). https://doi.org/10.1007/s10902-013-9490-3
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DOI: https://doi.org/10.1007/s10902-013-9490-3