## Diet Screener in the 2005 CHIS: Uses of Screener Estimates in CHIS

- Introduction
- Variance-Adjustment Factor
- Attenuation of Regression Parameters Using Screener Estimates
- References

### Introduction

Dietary intake estimates from the California Health Interview Survey (CHIS) Diet Screener are rough estimates of usual intake of fruits and vegetables and added sugar. They are not as accurate as more detailed methods (e.g. 24-hour recalls). However, validation research suggests that the estimates may be useful to characterize a population's median intakes, to discriminate among individuals or populations with regard to higher vs. lower intakes, to track dietary changes in individuals or populations over time, and to allow examination of interrelationships between diet and other variables. In addition, diet estimates from the CHIS could be used to augment national data using similar methods.

### Variance-Adjustment Factor

#### What is the variance adjustment estimate and why is it needed?

Data from the CHIS Diet Screener are individuals' reports about their intake and, like all self-reports, contain some error. The algorithms we use to estimate servings of fruits and vegetables and added sugar calibrate the data to 24-hour recalls. The screener estimate of intake represents what we expect the person would have reported on his 24-hour recall, given what he reported on the individual items in the screener. As a result, the mean of the screener estimate of intake should equal the mean of the 24-hour recall estimate of intake in the population. (It would also equal the mean of true intake in the population if the 24-hour recalls were unbiased. However, there are many studies suggesting that recalls underestimate individuals' true intakes).

When describing a population's distribution of dietary intakes, the parameters needed are an estimate of central tendency (i.e., mean or median) and an estimate of spread (i.e., variance). The variance of the screener, however, is expected to be smaller than the variance of true intake because the screener prediction formula estimates the conditional expectation of true intake given the screener responses, and in general, the variance of a conditional expectation of a variable X is smaller than the variance of X itself.

As a result, the screener estimates of intake cannot be used to estimate quantiles (other than median) or prevalence estimates of true intake unless it is first adjusted so that it has approximately the same variance as true intake.

#### When is it appropriate to use variance adjustment estimates?

The appropriate use of the screener information depends on the analytical objective. Following is a characterization of suggested procedures for various analytical objectives.

Analytical Objective | Procedure |
---|---|

Estimate mean or median intake in the population or within subpopulations. | Use the unadjusted screener estimate of intake. |

Estimate quantiles (other than median) of the distribution of intake in the population; estimate prevalence of attaining certain levels of dietary intake. | Use the variance-adjusted screener estimate. |

Classify individuals into exposure categories (e.g., meeting recommended intake vs. not meeting recommended intake) for later use in a regression model. | Use the variance-adjusted screener estimates to determine appropriate classification into categories. |

Use the screener estimate as a continuous covariate in a multivariate regression model. | Use the unadjusted screener estimate. |

#### How were the variance adjustment factors estimated?

We developed procedures to estimate the variance of true intake using data from 24-hour recalls, by taking into consideration within-person variability^{1, 2}. We extended these procedures to allow estimation of the variance of true intake using data from the screener. The resulting variance adjustment factors adjust the screener variance to approximate the variance of true intake in the population.

We used two external validation datasets available to us to estimate the adjustment factors: the Eating at America's Table Study (EATS) and the Observing Protein and Energy Nutrition Study (OPEN). The results indicate that the adjustment factors differ by gender for each dietary variable. Under the assumption that the variance adjustment factors appropriate to the California Health Interview Survey are similar to those in these external studies, the variance-adjusted screener estimates of intake should have variances closer to the estimated variance of true intake than would have been obtained from repeat 24-hour recalls.

Dietary Variable | Variance Adjustment Factors | ||
---|---|---|---|

Men | Women | ||

Total fruits and vegetables (includes French fries and dried beans) | Pyramid servings | 1.3 | 1.1 |

cup equivalents | 1.2 | 1.1 | |

Fruits and vegetables without French fries | Pyramid servings | 1.3 | 1.1 |

cup equivalents | 1.2 | 1.1 | |

Fruits and vegetables without dried beans | Pyramid servings | 1.2 | 1.1 |

cup equivalents | 1.2 | 1.1 | |

Fruits and vegetables without French fries and dried beans | Pyramid servings | 1.3 | 1.1 |

cup equivalents | 1.2 | 1.1 | |

Added sugar (tsp) | 1.5 | 1.3 |

#### How are the variance adjustment factors applied?

Adjust the screener estimate of intake by:

- multiplying intake by an adjustment factor (an estimate of the ratio of the standard deviation of true intake to the standard deviation of screener intake); and
- adding a constant so that the overall mean is unchanged.

The formula for the variance-adjusted screener is:

variance-adjusted screener = (variance adjustment factor)*(unadjusted screener - mean_{unadj scr.}) + mean_{unadj scr.}

This procedure is performed on the normally distributed version of the variable (i.e., Pyramid servings of fruits and vegetables is square-rooted; teaspoons of added sugar is cube-rooted). The results can then be back-transformed to obtain estimates in the original units.

A similar variance adjustment procedure is used to estimate prevalence of intakes for the 2000 NHIS in:

- Thompson FE, Midthune D, Subar AF, McNeel T, Berrigan D, Kipnis V. Dietary intake estimates in the National Health Interview Survey, 2000: Methodology, results, and interpretation.
*J Am Dietet Assoc*2005;105:352-63.

### Attenuation of Regression Parameters Using Screener Estimates

When the screener estimate of dietary intake is used as a continuous covariate in a multivariate regression, the estimated regression coefficient will typically be attenuated (biased toward zero) due to measurement error in the screener. This "attenuation factor"^{3} can be estimated in a calibration study and used to deattenuate the estimated regression coefficient (by dividing the estimated regression coefficient by the attenuation factor).

We estimated attenuation factors in the EATS and OPEN data (see the following table).

Dietary Variable | Attenuation factors for screener-predicted intake | ||
---|---|---|---|

Men | Women | ||

(Square-root) Total fruits and vegetables | Pyramid servings | 0.81 | 0.66 |

cup equivalents | 0.79 | 0.63 | |

(Square-root) Fruits and vegetables without French fries | Pyramid servings | 0.87 | 0.69 |

cup equivalents | 0.84 | 0.65 | |

(Square-root) Fruits and vegetables without dried beans | Pyramid servings | 0.78 | 0.65 |

cup equivalents | 0.78 | 0.63 | |

(Square-root) Fruits and vegetables without French fries and dried beans | Pyramid servings | 0.85 | 0.69 |

cup equivalents | 0.83 | 0.65 | |

(Cube-root) Added sugar | 0.95 | 0.89 |

If the screener values are categorized into quantiles and the resulting categorical variable is used in a linear or logistic regression, the bias (due to misclassification) is more complicated because the categorization can lead to differential misclassification in the screener^{4}. Although methods may be available to correct for this^{5, 6}, it is not simple, nor are we comfortable suggesting how to do it at this time.

Even though the estimated regression coefficients are biased (due to measurement error in the screener or misclassification in the categorized screener), tests of whether the regression coefficient is different from zero are still valid. For example, if one used the SUDAAN REGRESS procedure with fruit and vegetable intake (estimated by the screener) as a covariate in the model, one could use the Wald F statistic provided by SUDAAN to test whether the regression coefficient were statistically significantly different from zero. This assumes that only one covariate in the model is measured with error; when multiple covariates are measured with error, the Wald F test that a single regression coefficient is zero may not be valid, although the test that the regression coefficients for all covariates measured with error are zero is still valid.

### References

National Research Council. Nutrient Adequacy: Assessment Using Food Consumption Surveys. Washington, DC: National Academy Press, 1986.

Institute of Medicine. Dietary Reference Intakes: Applications in Dietary Assessment. Washington, DC: National Academy Press, 2000.

Rosner B, Willett WC, Spiegelman D. Correction of logistic regression relative risk estimates and confidence intervals for systematic within-person measurement error. *Stat Med* 1989;8:1051-69.

Flegal KM, Keyl PM, Nieto FJ. Differential misclassification arising from nondifferential errors in exposure measurement. *Am J Epidemiol* 1991;134:1233-44.

Flegal KM, Brownie C, Haas JD. The effects of exposure misclassification on estimates of relative risk. *Am J Epidemiol* 1986;123:736-51.

Morrissey MJ, Spiegelman D. Matrix methods for estimating odds ratios with misclassified exposure data: extensions and comparisons. *Biometrics* 1999;55:338-44.