The objective of this paper is to measure the impact of first-pillar public pensions spending on the prevalence of poverty among the elderly. Using data from 27 European countries from 1995 to 2014, we estimate the elasticity of the poverty rate among individuals aged over 65 years to per capita public pensions spending. We show the existence of a nonlinear relationship between these two variables. The elasticity is negative and statistically different from 0 only beyond a level of spending of 685€ per capita. At the average value of 2819€, it is estimated that the elasticity is around − 1.45. This nonlinear relationship is robust to the treatment of possible endogeneity and to different robustness checks like the variation of the poverty line as well as to the inclusion of country-specific differences in public pension plans.
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The 15 OECD countries are Austria, Belgium, Denmark, Finland, France, Germany, Greece, Ireland, Italy, Luxembourg, Netherlands, Portugal, Spain, Sweden, UK.
The red curve is the result of a linear regression with expenditures and squared expenditures as explanatory variables. The source and an exhaustive description of the variables are provided in Table 9 of Appendix 1. On the top left of the graph are clustered countries such as Cyprus, Ireland and Latvia, and at the bottom right are Luxembourg and Denmark.
Equivalent disposable income is the total income of a household available to consume or save, after taxes and transfers, divided by the number of individuals in the household. Each individual is transformed into an adult equivalent.
About the interest of considering relative poverty rates (i.e. a threshold defined in relation to the median or mean income of each country for a given year) rather than absolute ones, see Bourguignon (2003). This is quite standard in the literature; see Cantillon (2011), Caminada et al. (2012), Caminada and Goudswaard (2012), van Vliet et al. (2012), Been et al. (2016) which also opt for a relative indicator to measure poverty.
See for instance Foster et al. (1984) which compute a poverty measure that is sensitive to income distribution and accounts for the aversion to poverty. Related to this point, Marchand and Smeeding (2016) point out that the poverty rate is not able to account for all poverty dimensions, such as depth and duration of poverty. More recently, researchers (see for instance Lefèbvre et al. 2018) have also drawn attention to the “mortality paradox” and to the fact that standard poverty measures tend to underestimate actual poverty because of a simple selection effect induced by the positive correlation between income and survival (poorer people also die earlier). We abstract here from such considerations that would considerably complicate our computations.
For a complete definition, see Eurostat (2014) http://ec.europa.eu/eurostat/statistics-explained/index.php/Glossary:Expenditure_on_pensions.
For instance, in some European countries (like Denmark and the Netherlands), contributing to a private pension plan (occupational or not) is mandatory and it may account for an important part of the income of the retirees.
For a complete definition of means-tested benefits, see Eurostat (2014): http://ec.europa.eu/eurostat/statistics-explained/index.php?title=Glossary:Means-tested_benefits&oldid=324037.
Note that our results are robust to using Purchasing Power Standard instead of constant-2010 Euros.
We have also performed a regression adding a cubic term for the log of public pension expenditures. Since the coefficient associated with this term was very small and did not increase the explanatory power of the model, we decided to keep the regressions with only quadratic terms. Regressions including higher-order terms are available from the authors upon request.
Note that we also performed regression 3 including also year fixed effects. Since it did not qualitatively change our results, we decided not to report it.
Considering a relative measure for the poverty rate may be seen as a drawback of our analysis for this specific reason. However, using absolute measures has other drawbacks such as making more difficult to compare countries with different economic situations.
In unreported estimations, we also included the participation rates of individuals between 60 and 64, and of those aged 65 and older. Since the coefficients associated with these variables were found to be nonsignificant, we decided to drop them from the regressions.
We vary per capita expenditures from 100€ to 8000€ as the minimum per capita expenditures is 171.75€ and the maximum is 7658.28€ in our sample.
Although the value of elasticities is significantly different from zero, confidence intervals are large.
2819.45€ is computed as the average over the 1995–2014 period for each country, of per capita yearly public pensions.
In Appendix 5, Figure 7 plots the elasticity of poverty assuming away country fixed effects. We obtain the same decreasing and nonlinear pattern except that it becomes statistically significant around 400€ of per capita public pensions expenditures and that it stabilizes at a lower level, around \(-1.70\) at 8000€.
Section 4.4 reports additional robustness checks which, in particular, address the question of how the existence of (non) mandatory occupational plans or of (non) mandatory private plans could affect the baseline value of the elasticity.
See in particular Chapter 9, Sect. 9.5.
Recall that the relationship between poverty and per capita public pensions spending is not significant for a poverty line set at 40% of median income.
Note that, in some way, some of these differences are already taken into account when we include country fixed effects.
15% represents the higher bound, and it is computed as the average level of means-tested expenditures in our sample (\(4.4\%\)) plus one standard deviation (\(10.3\%\)).
Note that we could not obtain data over time so that we are not able to know whether some countries took reforms to promote occupational pension plans and/or private pension plans. Hence, we proceed as if these structures had not changed across years. Countries with mandatory or quasi-mandatory occupational pension plans are Belgium, Denmark, Sweden, Estonia, Ireland, Cyprus, Malta, Netherland, Austria, Portugal. Countries with mandatory or quasi-mandatory private pension plans are Bulgaria, Estonia, Croatia, Latvia, Lithuania, Poland, Romania, Slovakia, Sweden. See European Commission, Ageing report (2015), pp. 58.
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We thank Philippe De Donder, Raquel Fonseca, Mathieu Lefebvre, Florian Mayneris, Pierre Pestieau as well as participants to the 2017 CRDCN Conference in Montreal and participants to the Economic Department internal seminar at UQAM, for their comments and suggestions. We also thank an anonymous referee as well as the editor for their comments.
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Appendix 1: Country list and abbreviations
See Table 8.
Appendix 2: Definition and source of variables
See Table 9.
Appendix 3: Descriptive statistics
Appendix 4: Common trend in public pensions expenditures and in poverty rates
Appendix 5: Baseline regression without country-fixed effects
Appendix 6: Robustness: Leave-out countries and group of countries
See Table 16.
Appendix 7: Robustness: 2SLS with two-year lagged instruments
See Table 17.
Appendix 8: Robustness: Changing the definition of the poverty line
The following Table 18 presents specification (3) of the baseline scenario (see Table 1) when we vary the poverty line at 40, 50 and 60% of the median or of the mean income for the computation of the poverty rate.
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Jacques, P., Leroux, ML. & Stevanovic, D. Poverty among the elderly: the role of public pension systems. Int Tax Public Finance 28, 24–67 (2021). https://doi.org/10.1007/s10797-020-09617-2
- Income inequalities
- Public pension systems
- Panel data