Table 1.
Dataset | Outcome Studied: Test Scores (T), Schooling (S) |
Timing of Income (Developmental Stage of the Child at Which Income Effects are Studied) |
Separate the Effect of Income from Changes in Labor Supply or Family Environment |
Distinguishes the Effects of Contempora-neous vs Permanent Income |
Sources of Income Whose Effects are Studied |
Instrument Used | Effect of Income on Human Capital Investments |
|
---|---|---|---|---|---|---|---|---|
Carneiro and Heckman (2002) | NLSY79* | S | E and L College Enrollment | X | ✓ | Total family income | None |
|
Belley and Lochner (2007) | NLSY79*, NLSY97* | S | L High school completion and College Enrollment | X | X | Total family income | None | High school completion: +8.4% for highest income quartile compared to lowest in 79, +6.7 in 97 cannot reject equal effect of income; college enrollment: +9.3% for highest income quartile compared to lowest in 79, +16 in 97, cannot reject equal effect of income. |
Dahl and Lochner (2012) | NLSY79*, C-NLSY79* | T | E Preadolescence (ages 8 to 14) | Xa | Xb | Total family income | Policy variation in EITC eligibility | $1,000 extra per year for 2 years: +6% of a standard deviation in math and reading combined PIAT score. |
Duncan et al. (1998) | PSID* | Sd | E and L Childhood and Preadolescence (ages 0 to 15) | X | ✓ | Total family income | None | $10,000 increase in average (age 0-15) family income: +1.3 years of schooling in low income (<$20,000) families, +0.13 in high income ones. Relevance of income is stronger in the early years (age 0-5): $10,000 increase in average (age 0-5) family income leads to extra 0.8 years of schooling in low income families, 0.1 in high income ones. Income at age 6-10 and 11-15: no significant effect. Similar results in a sibling differences model. |
Duncan et al. (2011) | Randomized Interventions on Welfare Support | T | E Early Childhood (ages 2 to 5) | X | X | Total family income | Random assignment to programs offering welfare transfers conditional on employment or education related activities, or full time work | $1,000 extra per year for 2 to 5 years: +6% of a standard deviation in child’s achievement score. |
Loken (2010) | Norwegian Administrative Data | S | E Childhood (ages 1 to 11) | ✓c | X | Total family income | Oil discovery (inducing regional increase in wages) | OLS: positive relationship of average (age 1-13) family income on children’s education, IV: no causal effect. Results are robust to different specification and splitting the sample by parental education. |
Loken et al. (2012) | Norwegian Administrative Data | S | E Childhood (ages 1 to 11) | X | X | Total family income | Oil discovery (inducing regional increase in wages) | Non-linear IV (quadratic model): increase of $17,414, +0.74 years of education for children in poor families, +0.05 for children in rich families.† |
Milligan and Stabile (2011) | CCTB**, NCBS*** | T | E Childhood (ages 0 to 10) | X | X | Child related tax benefits and income transfers | Variation in benefits eligibility | Low education mothers: positive effects of child benefits on cognitive outcomes for boys, on emotional outcomes for girls, weak on health. Results are non robust to the exclusion of Quebec. |
Carneiro et al. (2013) | Norwegian Registry | Se | E and L Childhood to Adolescence (ages 0 to 17) | X | ✓ | Total family income | None | All outcomes: monotone and concave relationship with permanent income. £100,000 increase in permanent father’s earnings: +0.5 years of schooling. Timing of income: a balanced profile between early (age 0-5) and late childhood (age 6-11) is associated with the best outcomes; shifting income to adolescence is associated with better outcomes in dropping out of school, college attendance, earnings, IQ and teen pregnancy. Early and late childhood income are complements in determining schooling attainment, early and adolescent income are substitutes. |
b: Studies of Credit Constraints | ||||||||
| ||||||||
Dataset | Outcome Studied: Test Scores (T), Schooling (S) |
Timing of Income (Developmental Stage of the Child at Which Constraints are Studied) |
Explicit Dynamic Model |
Who is Affected by Constraints: Parent of the Agent (P), Agent / Child (C) |
Method to Test for Credit Constraints |
Find Presence of Credit Constraints |
Effect of Income or Constraints on Human Capital Investments |
|
| ||||||||
Keane and Wolpin (2001) | NLSY79* | S | L College Enrollment | ✓ | C | Structural estimation of the lower bound on asset level | YES But irrelevant for schooling decisions | Increase borrowing limit to $3,000 (3× max estimated): no change in mean highest grade completed; +0.2% in college enrollment; -0.2$ on mean hourly wage rate; increase in consumption and reduction in market hours; moderate reduction in parental transfers especially for the least educated parents. |
Cameron and Taber (2004) | NLSY79* | S | L Adolescence and College Enrollment | X | C | IV estimation of “returns” to schooling using costs of schooling or foregone earnings as instruments | NO | Theoretical prediction: if borrowing constraints, IV estimates using direct costs of schooling higher than using opportunity costs. Data: IV estimates using the presence of a local college are smaller than the ones using foregone earnings. Regressions which interact college costs and characteristics potentially related to credit availability: no evidence of excess sensitivity to costs for potentially constrained sample. Structural model: almost 0%of the population is found to borrow at a rate higher than the market one. |
Caucutt and Lochner (2012) | NLSY79*, C-NLSY79* | Ta | E and L Childhood and Adolescence | ✓ | P | Structural estimation of the lower bound on asset level | YES Stronger effect on high skilled parents | 50% of young parents are constrained: high school dropouts (50%), high school graduates (38%), college dropouts (60%), college graduates (68%); and 12% of old parents are constrained. Families with college graduate parents benefit the most from a reduction in credit constraints. |
E refers to “early” years (childhood), L refers to “late” years (adolescence).
Control for labor supply, but endogeneity is not considered,
Only analysis of past versus contemporaneous income,
Labor supply is not modeled, but the effects of the instrument on it are studied and found insignificant,
Hazard of non marital birth is also studied,
Other outcomes (health, teenage pregnancy, IQ) are studied as well.
NLSY79: National Longitudinal Survey of Youth 1979, NLSY97: National Longitudinal Survey of Youth 1997, C-NLSY79: Children on the National Longitudinal Survey of Youth 1979, PSID: Panel Study of Income Dynamics;
Canada Child Tax Benefit;
National Child Benefit Supplement.
Unfortunately, this study is flawed by using an IV procedure for ordered choice models of schooling that counts outcomes for certain subsets of the population multiple times and is difficult to interpret economically (see Heckman et al. (2006)) for a critical discussion of the method used.
E refers to “early” years (childhood), L refers to “late” years (adolescence).
The consequences on child’s schooling outcomes are studied as well.
NLSY79: National Longitudinal Survey of Youth 1979, NLSY97: National Longitudinal Survey of Youth 1997, C-NLSY79: Children on the National Longitudinal Survey of Youth 1979.