Item discrimination indicates the extent to which success on an item corresponds to success on the whole test. Since all items in a test are intended to cooperate to generate an overall test score, any item with negative or zero discrimination undermines the test. Positive item discrimination is generally productive, unless it is so high that the item merely repeats the information provided by other items on the test. This is the "attenuation paradox."
The Discrimination Index (D) is computed from equal-sized high and low scoring groups on the test. Subtract the number of successes by the low group on the item from the number of successes by the high group, and divide this difference by the size of a group. The range of this index is +1 to -1. Using Truman Kelley's "27% of sample" group size, values of 0.4 and above are regarded as high and less than 0.2 as low by R.L. Ebel (1954, Procedures for the Analysis of Classroom Tests, Educational and Psychological Measurement, 14, 352-364).
The Point-biserial Correlation is the Pearson correlation between responses to a particular item and scores on the total test (with or without that item). The Biserial Correlation models the responses to the item to represent stratification of a normal distribution and computes the correlation accordingly. Again the ranges are +1 to -1. The biserial is always more extreme than the point-biserial. Jm Nunnally (Psychometric Theory, 1967, p. 123) states that "to use the biserial is to paint a faulty picture of the actual size of the correlations obtainable from existing data." A convenient substitute for these correlations, particularly when data are missing, is the correlation between the Rasch person measures and their responses to the item, the point-measure correlation.
The 2-PL model parameterizes item discrimination in the model and uses it to estimate person ability. A 2-PL model can be written:
At its core, the estimation process is:
Unconstrained, this produces a feed-back loop. In (2), success on highly discriminating items (Xni=1) raises the person measure, failure (Xni=0) lowers the person measure. In (3), success on an item by those with high measures, coupled with failure by those with low measures, raises the item discrimination. This raised discrimination then feeds back into (2) to increase the measure difference between the successful and unsuccessful, which then, in (3), increases the item discrimination, ad infinitum. To avoid this, 2-PL estimation programs introduce constraints such as a maximum limit on item discrimination estimates, and a pre-set person distribution. Rasch models have pre-set item discriminations in the model, so feedback does not occur. Person and item measures can be estimated in (2) because ai is set to 1 at this step. Then those measures can be used in (3) to estimate Rasch" item discriminations. There is no return to (2).
The plot shows the relationship between these indices. It reports item discrimination indices for dichotomous data reported in W J. Micheels and M. R. Karnes (1950, Measuring Educational Achievement, p. 478-9). For these data, the biserial correlations sometimes exceed 1, so that index is contra-indicated. The Discrimination Index (D) has been computed with the top 27% of the person sample in the high group and the bottom 27% in the low group. The trendlines (.... point-biserial, - - - discrimination index) show that all indices give similar information. The item ringed on left side of the plot has a low correlation but high Rasch item discrimination. It is an easy item with a few misfitting incorrect responses. The item ringed in the bottom left of the plot has negative Rasch discrimination. Its model and empirical ICCs are shown here. These results suggest that the point-measure or, for complete data, the point-biserial correlation capture the useful item discrimination information.
John M. Linacre
Note: the biserial correlation originated in Karl Pearson, "On a New Method of Determining Correlation ....", Biometrika, Vol. VII, pp. 96-105, 1909, and the point-biserial correlation originated in Richardson, M.W. & Stalnaker, J.M. (1933). "A note on the use of bi-serial r in test research". Journal of General Psychology, 8, 463-465.
|Item 31 (Micheels & Karnes)|
Discrimination, Guessing and Carelessness Asymptotes: Estimating IRT Parameters with Rasch.Linacre J.M. Rasch Measurement Transactions, 2004, 18:1 p.959-960
Item Discrimination Indices. Kelley T., Ebel R., Linacre, JM. Rasch Measurement Transactions, 2002, 16:3 p.883-4
|Rasch Measurement Transactions (free, online)||Rasch Measurement research papers (free, online)||Probabilistic Models for Some Intelligence and Attainment Tests, Georg Rasch||Applying the Rasch Model 2nd. Ed., Bond & Fox||Best Test Design, Wright & Stone|
|Rating Scale Analysis, Wright & Masters||Introduction to Rasch Measurement, E. Smith & R. Smith||Introduction to Many-Facet Rasch Measurement, Thomas Eckes||Invariant Measurement: Using Rasch Models in the Social, Behavioral, and Health Sciences, George Engelhard, Jr.||Statistical Analyses for Language Testers, Rita Green|
|Rasch Models: Foundations, Recent Developments, and Applications, Fischer & Molenaar||Journal of Applied Measurement||Rasch models for measurement, David Andrich||Constructing Measures, Mark Wilson||Rasch Analysis in the Human Sciences, Boone, Stave, Yale|
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|Sept. 30, 2014, Tues.||Submission deadline: 6th Rasch Conference: Sixth International Conference on Probabilistic Models for Measurement in Education, Psychology, Social Science and Health, Cape Town, South Africa www.rasch.co.za/conference.php|
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