Abstract
Using data from the NLSY97, this paper re-examines the empirical relationship between household economic resources and youth criminal participation. Previous estimates of this relationship have often suggested this relationship to be quite weak or even non-existent. However, this analysis suggests that much of the strength of the relationship between household economic resources and youth criminal participation may be obscured due to non-linearities in this relationship, the fact that this relationship is isolated to crimes of a serious nature only, and especially because of measurement error with respect to measuring household economic resources. I show that adjusting for these issues substantially increases the estimated strength of this relationship. Indeed, the results in this paper show that the differences in serious criminal participation between youth from households in the upper parts of the income distribution and youth from households in the lower parts of the income distribution appear to be greater than the difference in serious criminal participation between genders.
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Notes
It should be emphasized the IV methods used in this paper are used to adjust for measurement error only, and are not meant to shed any light on the existence or magnitude of causal effects of household economic resources on youth criminal participation.
See Steffensmeier and Allan (1996) for a discussion of male/famale differences in criminality.
Technically, this “observation year” will be more than one year, as respondents in the sample used in this analysis were interviewed an average of 19.9 months after completing the first round interview. The length of this “observation year” does not appear to differ substantially across the household income distribution, with the mean length for the youth from the poorest third of the household wealth distribution averaging 20.0 months between the first and second round interviews, youth from the middle third of the household wealth distribution averaging 19.7 months between interviews, and youth from the richest third of the household wealth distribution also averaging 19.8 months between interviews. Therefore, while observation year for youth from the poorest third of the household wealth distribution does cover activity over a slightly longer period of time, the difference works out to only about 3/10 of a month or 9 days.
A few individuals refused to answer a crime question or answered “don’t know.” However, since all of these respondents who refused to answer or answered “don’t know” to a particular crime question answered in the affirmative to a different crime question, it does not matter whether these ambiguous responses are treated as affirmatives or negatives since I will only be looking at whether an individual participated in a crime during the time between the first and second round interviews.
Individuals who were not interviewed in the second round or for which there was no data on household income and/or wealth from 1997 were dropped from the sample used for this analysis. This latter criteria left 5,577 of the 8,386 NLSY97 individuals who had second round interviews. As shown in Appendix Table 4, these individuals who were excluded from the analysis appear to be generally similar to those remaining in the analysis with respect to numerous characteristics. Moreover, all OLS regression results remains essentially unchanged if these individuals are kept in the sample and multiple imputation is used to account for the missing data (results available from the author upon request).
All regression results reported in this paper are weighted using the NLSY97 individual weights, and standard errors clustered at the household level.
The actual cutoffs were $19,000 for the second quintile and $51,000 for the fourth quintile.
Interestingly, the estimated coefficient is actually significantly positive for Hispanic youth with respect to participation in minor crime.
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Bjerk, D. Measuring the Relationship Between Youth Criminal Participation and Household Economic Resources. J Quant Criminol 23, 23–39 (2007). https://doi.org/10.1007/s10940-006-9017-8
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DOI: https://doi.org/10.1007/s10940-006-9017-8