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Erschienen in: Prevention Science 1/2006

01.03.2006

Assessing the Total Effect of Time-Varying Predictors in Prevention Research

verfasst von: Bethany Cara Bray, Daniel Almirall, Rick S. Zimmerman, Donald Lynam, Susan A. Murphy

Erschienen in: Prevention Science | Ausgabe 1/2006

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Abstract

Observational data are often used to address prevention questions such as, “If alcohol initiation could be delayed, would that in turn cause a delay in marijuana initiation?” This question is concerned with the total causal effect of the timing of alcohol initiation on the timing of marijuana initiation. Unfortunately, when observational data are used to address a question such as the above, alternative explanations for the observed relationship between the predictor, here timing of alcohol initiation, and the response abound. These alternative explanations are due to the presence of confounders. Adjusting for confounders when using observational data is a particularly challenging problem when the predictor and confounders are time-varying. When time-varying confounders are present, the standard method of adjusting for confounders may fail to reduce bias and indeed can increase bias. In this paper, an intuitive and accessible graphical approach is used to illustrate how the standard method of controlling for confounders may result in biased total causal effect estimates. The graphical approach also provides an intuitive justification for an alternate method proposed by James Robins [Robins, J. M. (1998). 1997 Proceedings of the American Statistical Association, section on Bayesian statistical science (pp. 1–10). Retrieved from http://​www.​biostat.​harvard.​edu/​robins/​research.​html; Robins, J. M., Hernán, M., & Brumback, B. (2000). Epidemiology, 11(5), 550–560]. The above two methods are illustrated by addressing the motivating question. Implications for prevention researchers who wish to estimate total causal effects using longitudinal observational data are discussed.
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Fußnoten
1
In this paper, we assume that all variables in the subset \(\mathbf{O}\) are measured precisely. Consequently, we consider neither measurement error nor measurement models.
 
2
This model makes the proportional hazards assumption that the effect of alcohol initiation is the same at all time points. This modeling assumption is maintained throughout the paper; it has no bearing on the causal issues that are discussed throughout.
 
3
If an arrow from Alc\(_1\) to PPress\(_2\) were present in Fig. 1, Panel A, then \(\beta_1\) in Eq. (2) would be interpreted as the direct causal effect of alcohol initiation on marijuana initiation.
 
4
In addition, \(\beta_1\) would be interpreted as the direct causal effect of alcohol initiation on marijuana initiation. For simplicity and reasons of space, this is not elaborated upon in this paper.
 
5
Here, PPress\(_2\) is known as a collider in Panel B of Fig. 2 because it is affected by the \(\mathbf{U}_t\)s and Alc\(_1\). As Pearl notes, conditioning on colliders has the effect of inducing noncausal relations among parents of the collider (the \(\mathbf{U}_t\)s and Alc\(_1\)) that are otherwise not related causally. Because we are unable to condition further on the unobserved or unknown variables (the \(\mathbf{U}_t\)s) in our setting, the induced noncausal relations become part of the observed relation between the collider's observed parent (Alc\(_1\)) and the response (Mj\(_2\)).
 
6
The weighting method is also known as inverse-probability-of-treatment-weighting, or IPTW, where “treatment” refers to the exposure or putative cause.
 
7
The analyses presented here include only those participants who had no missing data on heart rate, performance IQ, verbal IQ, average sensation seeking, first peer pressure resistance measurement, and time of initiation of alcohol, cigarettes, conduct disorder, and other drug use. Therefore, this sample may not be representative of any subset of adolescents.
 
8
Last observation carried forward (LOCF) imputation was used only for peer pressure resistance because it was the only time-varying variable for which there was missing data among the participants in these analyses.
 
9
Sensation Seeking is conceived as a relatively stable personality trait (Zuckerman, 1994), thus, the average score across assessments is used in these analyses. Empirically, sensation seeking is quite stable; in the larger sample from which these data are drawn, the 1-year stabilities for sensation seeking approach the maximum correlation possible given the reliabilities of the scales (average 1-year stability=.70).
 
10
Robins (1998) shows that confidence intervals according to the robust standard errors calculated in this way have coverage probability of at least 95%; that is, confidence intervals using this method are (possibly) conservative.
 
11
These assumptions, concerning unmeasured variables, are by definition not testable.
 
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Metadaten
Titel
Assessing the Total Effect of Time-Varying Predictors in Prevention Research
verfasst von
Bethany Cara Bray
Daniel Almirall
Rick S. Zimmerman
Donald Lynam
Susan A. Murphy
Publikationsdatum
01.03.2006
Verlag
Springer US
Erschienen in
Prevention Science / Ausgabe 1/2006
Print ISSN: 1389-4986
Elektronische ISSN: 1573-6695
DOI
https://doi.org/10.1007/s11121-005-0023-0

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