Abstract
The demographic shift experienced by developed countries inevitably results in a change in intergenerational relations. However, despite some attempts to evaluate intergenerational balance in quantitative terms, there is still a significant literature gap in this respect. This paper aims to propose a conceptual and empirical framework to measure intergenerational balance in a cross-country perspective which can serve for the comparative assessment of the outcomes of various policies. It addresses the research question in which countries selected generations are privileged over others in socio-economic terms. Our empirical study includes the investigation of the (relative) situation of different generations as well as comparisons of gender differences in terms of studied welfare state performance across generations to examine whether gender equality in some generations is more promoted than in others. As a criterion, we employ multivariate statistical analysis methods to group 25 European countries into clusters using the intergenerational balance in terms of poverty, income, housing, labour market, education and health. We distinguish four patterns in this respect: ‘Supporting young’, ‘Supporting adult’, ‘Discriminating against elderly’ and ‘Supporting elderly’. Our findings reveal that shifting the perspective from inputs to outcomes and including gender perspective gives a somewhat different picture of Europe in terms of intergenerational balance.
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Notes
The use of data from 2012, i.e. five years earlier than the base period, refers to GD_Unempyoung (due to data gaps) and GD_Unempadult (to ensure intra-country comparability in terms of the period with GD_Unempyoung), so it applies only to 2 out of 56 indicators used in the empirical analysis. This suggests a minimal impact on the final results of the study. Nevertheless, as additional analysis, we approximated the unemployment rate for males and females aged 15–19 using similar data for age groups 15–24 and 20–24 and formula: \({Unemp}_{15-24}={Unemp}_{15-19}\bullet {w}_{15-19}+{Unemp}_{20-24}\bullet {w}_{20-24}\), where \({w}_{15-19}\) and \({w}_{20-24}\) denote the weights calculated on the basis of data from 2012 reflecting the shares of unemployment rates for age groups 15–19 and 20–24 (i.e. shares correlated to the age structure of the population) in the unemployment rate for the 15–24 age group. Using the available data for the unemployment rate for males aged 15–19 in 2014 and 2015 and females in 2013, approximation accuracy was measured. As absolute differences between empirical and approximated data were not greater than 1.5 pp (and not greater than 3.6% in relative terms), we used approximated unemployment rates for a robustness check. We compared the final results of the study obtained with data from 2012 for unemployment rates for males and females aged 15–19 with the approximated ones. There were not any differences in the clustering (both hierarchical and finally k-means) of the countries and in the results of ANOVA. In the case of the 20–64 age group, a quite stable difference between the unemployment rate for females and males is observed (-2.1, -1.5, -1.9, -2.5, -2.4 and -1.8 between 2012 and 2017). Thus, the use of data from 2012 instead of 2017 does not make a significant difference. As a consequence, we decided to include Latvia in the analysis despite relatively old data on the mentioned unemployment rates.
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This work was supported by the National Science Centre (Poland) [Grant number 2016/23/B/HS4/01772].
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Appendix
Appendix
See Tables
5,
6,
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9.
Example 1
To illustrate this problem of the sensitivity to the demographic structure with reference to the measurement of relative position of each generation (ratios in Table 6: RPR, RSMD, RMI, RS80/S20, RHCO, RMHC, ROR, RUnemp, REdu, RUMN) and justify our assumption that the ratios should not account for the demographic differences between countries, we present below a simplified example, where we apply the formula expressing the relative position of a given population in terms of the poverty rate.
Let’s assume that there are two countries A and B. In both countries, the corresponding generations have the same poverty rates (PR) given in %, i.e.:
PRA <18 = PRB <18 = 20.
PRA 18–64 = PRB 18–64 = 20.
PRA ≥65 = PRB ≥65 = 40.
We can observe that elderly generations in both countries have poverty rates two times greater than young and working-age generations. We can also see that in both countries the situation is precisely the same. Intuitively, we assess both countries as equal in terms of the poverty situation of each generation as compared to the remaining generations.
Now, when constructing the indicator of the relative position of a given population in terms of poverty rate, i.e. RPR, let us compare the two approaches:
First—sensitive to the age structure:
where PRtotal is the poverty rate reported for the total population in the country.
Second—insensitive to the age structure:
where PRmean is obtained according to the formula (PR < 18 + PR18−64 + PR ≥ 65)/3.
Additionally, let’s assume that the age structure in country A is:
Proportion of young generation A = 10% (of the total population).
Proportion of working-age generation A = 80%
Proportion of elderly A = 10%
and in country B:
Proportion of young generation B = 25% (of the total population).
Proportion of working-age generation B = 25%
Proportion of elderly B = 50%
As a result of such different demographic structures, poverty rates for the total population PRtotal, in both countries will significantly vary as they are affected by the strong prevalence of different generations (in country A—working-age, in country B—elderly):
(to simplify, we calculate PRtotal as PR average weighted by age structure) PRA total = 22, whereas PRB total = 30.
This way, in the first approach, we obtain:
For country A –
For country B –
Thus, if we apply the age-structure sensitive measurement, the indicators of the relative position reveal entirely different pictures of both countries. At the beginning of this example, we observed that equally in both countries elderly generation has the poverty rate two times greater than the remaining generations, but after including age structures, in country B, the situation of the elderly seems to be significantly better than in country A, which is a misleading conclusion. Consequently, we perceive the impact of the demographic structure as a bias of the analysis, and we employ the measurement free from this impact.
In the second approach, when we replace the denominator PRtotal with PRmean we will obtain precisely the same results for both countries, which adequately reflects the similarity of both countries:
For countries A and B –
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Chybalski, F., Marcinkiewicz, E. A Multidimensional Approach to Intergenerational Balance Measurement: A Cross-Sectional Study for European Countries. Soc Just Res 35, 206–241 (2022). https://doi.org/10.1007/s11211-022-00392-5
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DOI: https://doi.org/10.1007/s11211-022-00392-5