Abstract
This study focuses on the long-term trend in happiness by income level in the United States. General Social Survey data suggest that in the past, rich and poor Americans were not only more equal in terms of income, but also in terms of their subjective wellbeing: the happiness gap between the poor and the rich has been increasing. Today’s poor suffer greater relative unhappiness than the poor of past decades. The gap between the poor and the rich is substantial, approximately 0.4 on a 1–3 happiness scale. The increase in the happiness gap is striking: comparing the 1970s to the 2000s, the gap has widened by about 40 % between the poor and the rich, and by about 50 % between the middle class and the rich.
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Notes
We use the terms subjective wellbeing and happiness interchangeably. Happiness, life satisfaction, and subjective wellbeing do overlap. Although they are to some degree distinct, in the happiness literature it is customary to treat these concepts interchangeably (see e.g., Veenhoven 2008; Frey and Stutzer 2002; Diener and Lucas 1999; Radcliff 2013).
There was a lively discussion between Veenhoven and Delhey, and it resulted in many papers (http://scholar.google.com/scholar?q=veenhoven+delhey+inequality). This debate, however, is beyond the scope of this article, which deals with the US and changes over time, not cross-sectional comparisons across countries. The results of the present study do not necessarily conflict with Berg and Veenhoven (2010), who found that across nations there is no correlation between income inequality and average happiness. It is even possible that income inequality can add to average happiness in many countries by increasing the pie, though probably not anymore in the US—some economists think that current levels of inequality in the US are bad for the economy. Income inequality can actually hurt the economy, not only society (The Economist 2012a, b, 2013). Stevenson and Wolfers (2008) found happiness inequality to be decreasing, but they did not establish a connection with income inequality. Easterlin (2001) focused on happiness by income, but only at one point in time. Blanchflower and Oswald (2004) looked at change over time, but at the effect of income on happiness, not on the effect of income inequality on happiness inequality.
General reduction of inequality in happiness or reduction between some two groups, say racial groups, can co-exist with increasing inequality in the happiness across income groups. Taking Using a public health analogy, the life expectancy gap between Blacks and Whites has decreased but the life expectancy gap between the educated and the uneducated has increased (Meara et al. 2008).
We are grateful for this suggestion to an anonymous reviewer who pointed out a need: “to find a convincing way of handling trends other than the increase in inequality, which may be causing changes in the level and distribution of happiness.”
However, the Easterlin Paradox is observed in many countries, and our explanation may not hold up across the board—we are grateful for this point to Richard Easterlin.
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We thank Ruut Veenhoven. We take full responsibility for any errors or weaknesses that remain.
Appendices
Appendix 1: Additional Descriptive Statistics
See Figs. 3, 4, 5, 6 and Tables 3, 4, 5.
Appendix 2: Other Variables by Income Quintiles Over Time
Appendix 3: Happiness by Original Income Measures
See Fig. 10.
Appendix 4: Comparison of Inequality Measures from GSS and from Census
Gini data from the Census Bureau come from Table F-4 “Gini Indexes for Families, by Race and Hispanic Origin of Householder: 1947 to 2014,” available at https://www.census.gov/hhes/www/income/data/historical/inequality. Note that this gini index is for families (in this paper we use family income from the GSS). Furthermore, it is worth noting that from 1947 until 1972, when the GSS series began, the gini decreased only slightly and reached a low of 0.348 in 1968 before increasing, through to the present day. Data are plotted in graph 1. The correlation between the two series is 0.85. There is a spike in the GSS gini, another reason to rerun the analyses without the post-recession years. Yet, both series show a virtually identical linear trend as shown by fitted values (Fig. 11).
Data on income quintiles from the GSS and the Census are shown in Figs. 12 and 13. The Census data use 2011 constant dollars. The GSS uses 1986 constant dollars. The quintiles are more uneven for the GSS series. Incomes are estimates in the GSS and, for many years, not very continuous but rather, are presented more discretely. This limitation is unfortunate, particularly because these are the only data available that are consistent series and go back as far in time. The series are especially inconsistent in earlier years when there were fewer income categories, and so the cutoff points for quantiles are coarser. The fit between the two series is not close; to check whether the results might have been due to quantization, we reran the analyses using 3 and 7 classes (see “Appendix 5”). Results are similar.
Appendix 5: Robustness Checks: Using 3 and 7 Classes
Stata (the statistical software used in this study) performs quantization (assigns variable values into quantiles) in a peculiar way by checking whether it passes the appropriate percentile for given quantile and if it does not, it uses the lower quantile for categorization. This yields non-optimal cutoff points when a variable has few levels. For instance, in 1972 real income has the following distribution:
Income | Frequency | Percent | Cumulative percent |
---|---|---|---|
2707 | 123 | 8.34 | 8.34 |
8122 | 165 | 11.19 | 19.54 |
13,537 | 160 | 10.85 | 30.39 |
18,951 | 160 | 10.85 | 41.25 |
24,366 | 192 | 13.03 | 54.27 |
30,458 | 217 | 14.72 | 69 |
37,226 | 159 | 10.79 | 79.78 |
43,994 | 103 | 6.99 | 86.77 |
50,763 | 63 | 4.27 | 91.04 |
60,915 | 67 | 4.55 | 95.59 |
74,452 | 33 | 2.24 | 97.83 |
109,355 | 32 | 2.17 | 100 |
Total | 1474 | 100 |
Hence, an optimal solution is to classify only the first two categories (2707, 8122) into the first quintile (they constitute 19.54 percent of the distribution), but Stata takes the third category as well (13,573), because it does not reach 20 % after taking the first two. This peculiar approach has been documented on the Stata listserv by Stata’s foremost expert Nick Cox http://www.stata.com/statalist/archive/2012-06/msg01193.html, and at http://www.stata.com/statalist/archive/2012-06/msg01187.html. An obvious question is what if the study’s result—that the poor and rich are more unequal in happiness—is due to this strange clustering? We use 3 and 7 bins as a robustness check. Results hold up as shown in Tables 6 and 7.
Appendix 6: Family Income Versus Personal Income
There are theoretical and technical reasons for using family income as opposed to individual income, but for robustness, we discuss here the results using personal income. With respect to family income reported here there is a rather smooth gradient: the richer the group, the smaller the decrease in happiness over time, and as a result the bigger the gap in happiness. With respect to respondents’ income, this is still true when comparing the first quintile to the others: the poorest people became less happy over time. Richer groups remained more flat in their happiness, so the happiness gap between the poorest and the rest has increased. The key difference in results when using personal income is that all richer income groups remained at about the same happiness levels over time, so whatever happiness differences there were in the 1970s, they remained after the 2000s. In addition, the very richest group became slightly less happy, though not nearly by as much as the poorest group. The three middle quintiles remained most stable over time. For the reasons mentioned above, family income is a better measure, and we base our overall conclusions on the family income variable. These results do not generalize entirely when using personal income. In particular, the happiness gap between the richest and middle class has not increased if individual income is used instead of family income.
Finally, we reran models using family income divided by the natural log of the number of people in the household +1 (to avoid zero from ln(1)). The effect of family income on happiness depends in part on the number of people in a household. The rationale for dividing family income by the natural log of the number of people in a household is to scale the effect to reflect the diminishing marginal effect of each additional member of a household on family income (the addition of each subsequent member of a household “costs” less).
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Okulicz-Kozaryn, A., Mazelis, J.M. More Unequal in Income, More Unequal in Wellbeing. Soc Indic Res 132, 953–975 (2017). https://doi.org/10.1007/s11205-016-1327-0
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DOI: https://doi.org/10.1007/s11205-016-1327-0