106 CHAPTER 5
Table 5.4 Impact of future mortality on adolescent enrollment, 1998 Explanatory variable
(1) (2) Prime-age deaths (20–64 years)
0.1546 0.1653 (0.50)
(0.53)
Prime-age working deaths (20–64 years) –0.9943 –0.6800 (2.02)
(1.06) × Male Prime-age deaths (20–44 years) × Male Male prime-age deaths (20–44 years) × Male Female prime-age deaths (20–44 years) × Male
Number of observations Pseudo R2
524 524 0.4291 0.4316
–0.8699 (1.19)
–0.6470 –0.2600 (2.50)
(0.86)
–1.0060 (2.18)
–0.0674 0.5184 (0.19)
(1.17)
–1.3810 (2.30)
–1.1911 –0.8935 (3.35)
(1.91)
–0.8477 (1.31)
524 524 524 524 0.4313 0.4380 0.4417 0.4495
Sources: University of KwaZulu-Natal / International Food Policy Research Institute / University of Wisconsin–Madison (1998, 2004).
Notes: The dependent variable equals one if the individual was in school in 1998 and zero otherwise. Probit estimation used. The numbers in parentheses are absolute z-values. Robust standard errors are used with household-level clusters. The sample uses individuals aged 14–19 years in 1998, with the highest completed years of schooling strictly above zero. All specifications also include age in 1998; the value of durable goods in 1998; the number of household members in 1998 in age groups 0–4, 5–9, 10–14, 15–19, 20–24, 25–29, 30–34, 35–39, 40–44, 45–49, 50–54, 55–59, 60–64, and 65 years or above who have lived more than 15 days in the household in the previous month; and both grade (1998) and cluster fixed effects. Except for cluster fixed effects, these variables are interacted with a male dummy. The specifications include parental deaths in 1998–2001, but the effect was not estimable because of the small incidences of paren- tal deaths in the three-year period 1998–2001.
cluster (community) dummies and age to control observable heterogeneity, possibly determining schooling progression and transition to the labor market. Since in our sample all children under age 13 were enrolled in schools, I do not include those children. Column 1 includes deaths of prime-age (20–64) members and prime-age working members. In the preliminary analysis, I included mother’s and father’s deaths in 1998–2001, but the number of observations is so few that it was not feasible to estimate their effects. Adding both values to arrive at total parental deaths did not help estimate their effects.
The prime-age (20–64) deaths on their own do not affect enrollment sig- nificantly, but those of working members significantly decrease enrollment.
(3) (4) (5)
(6)
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