subjects were 370 undergraduate students of midwifery and nursing ( 48% female and 52%male ) selected from tabriz university of medical sciences . then , participants completed the questionnaires on their own . after completing the questionnaires , participants handed them to the researchers directly . the whoqol - bref is a 26-item instrument consisting of four domains : physical health ( 7 items ) , psychological health ( 6 items ) , social relationships ( 3 items ) , and environmental health ( 8 items ) ; it also contains qol and general health items . each individual item of the whoqol - bref is scored from 1 to 5 on a response scale , which is stipulated as a five - point ordinal scale . the physical health domain includes items on mobility , daily activities , functional capacity , energy , pain , and sleep . the psychological domain measures include self - image , negative thoughts , positive attitudes , self - esteem , mentality , learning ability , memory concentration , religion , and the mental status . the social relationships domain contains questions on personal relationships , social support , and sex life . the environmental health domain covers issues related to financial resources , safety , health and social services , living physical environment , opportunities to acquire new skills and knowledge , recreation , general environment ( noise , air pollution , etc . ) , and transportation ( 7 ) . because the whoqol - bref has a polytomous response format with the response options graded , an irt model appropriate for this item response format is samejima 's 1969 graded responses model ( grm ) . the grm conceptualizes an item in terms of a series of k1 or mi response dichotomies , where k is the number of response options . thus , if there are four response options , there will be three response dichotomies ; namely , the first category versus all other categories , the first and second response categories versus the third and fourth response categories , and first three response categories versus the fourth category . the trace lines reflecting these comparisons , are referred to as operator characteristic curves ( occs ) , which represent the probability of an examinees ' raw item response falling in or above a given category threshold conditional on the trait level (  ) . each occ provides the location of the appropriate threshold parameters ( b ) , which is the trait (  ) level where there is a 1.5 probability of endorsing the relevant response option or higher response options . the number of  's for an item will correspond to the number of response dichotomies . in the grm , the discrimination parameter ( a ) for all response options of an item is constrained to be equal . this constraint is not imposed across items . thus , each item will have its own single discrimination parameter . once the threshold and discrimination parameters for the different response dichotomies of an item are known , the probability of response to each response option in the item as a function of the underlying trait can be generated . the crc for the first response option will be a monotonically decreasing logistic function , while the crc for the last response option will be a monotonically increasing logistic function . the crcs for the other response options will all be nonmonotonic logistic functions . therefore , this study used samejima 's ( 18 ) grm . unidimensionality was tested using cronbach 's alpha , confirmatory factor analysis and exploratory factor analysis procedures . in relation to the exploratory procedures , parallel analysis ( 20 ) , followed by principal component analysis ( pca ) the pa procedure is known to provide more accurate results for the number of factors to be extracted than the eigenvalue greater than 1 ( or k1 ) rule or the scree test ( 21 ) . the ratio of the eigenvalues of the first and second unrotated components from the real data sets can also be used for evaluating unidimensionality , with high ratios being indicative of unidimensionality . the cfa approach involved testing the fit of 1-factor models for the whoqol - bref scale . fit was examined using the incremental fit index ( ifi ) and the comparative fit index ( cfi ) . subjects were 370 undergraduate students of midwifery and nursing ( 48% female and 52%male ) selected from tabriz university of medical sciences . the whoqol - bref is a 26-item instrument consisting of four domains : physical health ( 7 items ) , psychological health ( 6 items ) , social relationships ( 3 items ) , and environmental health ( 8 items ) ; it also contains qol and general health items . each individual item of the whoqol - bref is scored from 1 to 5 on a response scale , which is stipulated as a five - point ordinal scale . the physical health domain includes items on mobility , daily activities , functional capacity , energy , pain , and sleep . the psychological domain measures include self - image , negative thoughts , positive attitudes , self - esteem , mentality , learning ability , memory concentration , religion , and the mental status . the social relationships domain contains questions on personal relationships , social support , and sex life . the environmental health domain covers issues related to financial resources , safety , health and social services , living physical environment , opportunities to acquire new skills and knowledge , recreation , general environment ( noise , air pollution , etc . ) , and transportation ( 7 ) . because the whoqol - bref has a polytomous response format with the response options graded , an irt model appropriate for this item response format is samejima 's 1969 graded responses model ( grm ) . the grm conceptualizes an item in terms of a series of k1 or mi response dichotomies , where k is the number of response options . thus , if there are four response options , there will be three response dichotomies ; namely , the first category versus all other categories , the first and second response categories versus the third and fourth response categories , and first three response categories versus the fourth category . the trace lines reflecting these comparisons , are referred to as operator characteristic curves ( occs ) , which represent the probability of an examinees ' raw item response falling in or above a given category threshold conditional on the trait level (  ) . each occ provides the location of the appropriate threshold parameters ( b ) , which is the trait (  ) level where there is a 1.5 probability of endorsing the relevant response option or higher response options . the number of  's for an item will correspond to the number of response dichotomies . in the grm , the discrimination parameter ( a ) for all response options of an item is constrained to be equal . once the threshold and discrimination parameters for the different response dichotomies of an item are known , the probability of response to each response option in the item as a function of the underlying trait can be generated . the crc for the first response option will be a monotonically decreasing logistic function , while the crc for the last response option will be a monotonically increasing logistic function . unidimensionality was tested using cronbach 's alpha , confirmatory factor analysis and exploratory factor analysis procedures . in relation to the exploratory procedures , parallel analysis ( 20 ) , followed by principal component analysis ( pca ) the pa procedure is known to provide more accurate results for the number of factors to be extracted than the eigenvalue greater than 1 ( or k1 ) rule or the scree test ( 21 ) . the ratio of the eigenvalues of the first and second unrotated components from the real data sets can also be used for evaluating unidimensionality , with high ratios being indicative of unidimensionality . the cfa approach involved testing the fit of 1-factor models for the whoqol - bref scale . fit was examined using the incremental fit index ( ifi ) and the comparative fit index ( cfi ) . data were collected from 370 undergraduate students of nursing and midwifery(51.4% ) males and 170 females ( 45.9% ) . approximately 16.8% , ( n=52 ) of the subjects were living in rural areas , but the majority of them were living in cities ( 83.2% , n=190 ) . two primary assumptions of irt are unidimensionality of the scale , and local independence , which posits that when the respondent trait levels are controlled for , the items on the scale are independent from one another ( 11 , 21 ) . this unidimensionality is important because the basic samejima 's model assumes unidimensionality . in order to ensure this , we conducted a confirmatory factor analysis ( cfa ) on the 26 whoqol - bref items . a confirmatory factor analysis of the four a priori domain scales of the whoqol - bref improved fit over the one - factor model ( p < 0.001 ) . overall , model fit was good : bollen 's incremental fit index ( ifi ) = 0.940 , comparative fit index ( cfi ) = 0.939 , bentler - bonett normed fit index ( nfi ) = 0.933 and the factor loadings for each of the subscales ranged from 0.48 to 1.33 . 1 indicates , the whoqol was one - dimensional at baseline and at exit in that the observed first component was always smaller than that of generated from random data . the explorative factor analysis , parallel factor , in conjunction with the confirmatory factor analysis , meet the assumption of a general whoqol - bref dimension underlying each scale . scree plot of the whoqol - bref at baseline and exit with randomly generated scree ( parallel analysis 
 table 1 demonstrates five parameter estimates / items for all the items of the subscales of the whoqol bref one slope ( a ) , and four threshold separating the five response categories ( b0 , b1 , b2 , and b3 ) . irt parameter estimates for the scales of the 26-item whoqol bref -is the discrimination parameters -is the difficulty parameter in irt , these values of a can range from 0 to around 3 . they represent how quickly an item 's scores change as a function of changes in the latent trait . like factor loadings in a cfa , they capture how closely an item represents the latent trait being measured . as shown in this table , with the exception of item 15 , values of a for all items were large , although some are higher than others . based on baker 's ( 23 ) guidelines , fifteen items have moderate discrimination ( 3 , 4 , 7 , 1114 , 16 , 2026 ) , four items have high discrimination ( 6 , 9 , 18 , 19 ) , two items have very high discrimination ( 2 , 17 ) , and three items have perfect discrimination ( 5 , 8 , 10 ) . to get a sense of what the discrimination values mean , we can view the category response curves ( crc ) , which display how the score probabilities vary as a function of the latent curiosity trait . for the sake of illustration , fig . the crcs depict the probability that someone will respond to the item with a 1 , 2 , 3 , 4 , or 5 . the probability level is along the y - axis , and the level of trait quality of life , expressed as a standard normal distribution ( m=0 , sd=1 ) is along the x-axis.the different discrimination values are evident in the peaks and overlaps of the probability curves . illustration of category response and item response functions , and test information function ( continuous lines ) and standard error curves for the four scales of the quality of life . for the items 2 , 5 , 8 , 9 , 17 and 10 , which have a higher discrimination values , the response probabilities have higher peaks and have relatively less overlap . each scale value ( 1 through 5 ) has a region where its absolute probability is at least 50% , indicating that there are trait levels where that response is more probable than the other four options combined . for other items , in contrast , the response probabilities are flatter and overlap more significantly . for the middle three options ( 24 ) , the response curves are never higher than 0.50 . each item has five possible responses , so there are four response thresholds depicted as b1 , b2 , b3 , and b4 . in irt , these thresholds represent the trait levels at which someone has a 50% chance of scoring at or above a scale response . the value for b1 , the threshold between a response of 1 and a response of 2 , is -3.16 . this means that someone with a trait score of -3.16 , a pretty low level , has at least a 50% chance of responding to the item with a 2 , 3 , 4 , or 5 . conversely stated , a response of 1 is the most likely response for people with a quality of life less than -3.16 . the value for b2 , the threshold between the scores of 2 and 3 , is -2.02 . therefore , those with a quality of life score of -2.02 have at least a 50% chance of responding with a 3 , 4 , or 5 . on the whole the last threshold , b4 , is 0.84 , which is only around .12 sd above the mean . this means that a student with a quality of life greater than .84 has at least a 50% chance of responding with a 5 , the highest possible scale score . the difficulty thresholds are related to the frequency with which people chose different response options . item 25 , for example , has very high b4 threshold , and relatively few people responded with a 5 to the item . conversely , item 3 has very low b1 threshold , and relatively few people responded with a 1 to the item . for a self - report scale that measures individual differences , it is desirable for the items to offer information about a broad range of the trait . and others should be   harder .  an example of a relatively easy item is item 3-its lowest threshold is quite low , and only 1.1% of the sample responded with a 1 to it . only people who are very low in quality of life will respond with low scores to this item . a relatively harder item is item 15 : its highest threshold is 4.66 , so only people who are very high in quality of life will respond with a five . nevertheless , there is not much between - item variation in the difficulty ranges . each item covers a good range of the trait , but the items as a group tend to be centered at the trait 's midpoint . moreover , table 1 shows the threshold parameters ( b1 , b2 , b3 and b4 ) for all the personal items . as it is shown in this table , the b parameter values made noticeable increases in the level of the latent trait at each subsequent response dichotomy . also , the trait values for b1 , b2 and b3 were somewhat evenly spaced with all values below the mean trait level . for all items , the trait values for b4 were only slightly above the mean trait level . table 3 demonstrates the item information function values of the twenty six items in the whoqol bref scale . information for the items in the four scales of the spiritual well - being questionnaire as shown in this table , with the exception of item on 10 , the information values of all the items were quite low at all trait levels . figure 4 displays the test information function for the 4 quality of life scales . as can be seen in these plots , with the exception of items 10 , this indicates that the overall degree of measurement precision for these items is also relatively low . specifically , the items are less precise for measuring individuals with theta levels falling above 1.00 ( e.g. , 3 item ) and below-1(e.g . , 21 item ) . the test information functions ( tif ) provides information on the reliability of the whoqol - bref across the range of latent trait scores and is computed via a combination of location of the item and discrimination parameters . as noted by neal and colleagues ( 24 ) , when the total information curve is generally peaked , it indicates the highest degree of reliability the scale has at that level of the underlying latent trait score . as shown in fig.3 , the total information curve indicates that the whoqol bref has relatively moderate reliability . note that test information functions for the scale are relatively flat in the low range of  continuum . it does not have distinct peaks , but generally provides most information for  levels between zero and -2 ( measured in standard deviations ) . test information functions for whoqol bref scale appears to be the most evenly spread out across whole range of  continuum . indeed , this scale measures respondents with different levels of quality of life , from low to moderate , with almost equal precision . however , precision of the scale decreases sharply , while standard error of measurement increases sharply when respondents with high quality of life are measured . additional analyses focused on examining the reliability and validity of the refined whoqol bref via classical measurement techniques . for these analyses , classical test theory ( ctt ) statistics were conducted for the original 26-item whoqol bref . the cronbach 's alpha values for physical health , psychological health , social relationships and environmental health were 0.65 , 0.77 , 0.52 and 0.79 , respectively . the mean item - to - total correlations were 0.76 , 0.73 , 0.62 and 0.78 for physical health , psychological health , social relationships and environmental health , respectively . for each whoqol - bref , taken together , these findings support the unidimensionality of the four scales and the local independence of the items in each scale . data were collected from 370 undergraduate students of nursing and midwifery(51.4% ) males and 170 females ( 45.9% ) . approximately 16.8% , ( n=52 ) of the subjects were living in rural areas , but the majority of them were living in cities ( 83.2% , n=190 ) . two primary assumptions of irt are unidimensionality of the scale , and local independence , which posits that when the respondent trait levels are controlled for , the items on the scale are independent from one another ( 11 , 21 ) . this unidimensionality is important because the basic samejima 's model assumes unidimensionality . in order to ensure this , we conducted a confirmatory factor analysis ( cfa ) on the 26 whoqol - bref items . a confirmatory factor analysis of the four a priori domain scales of the whoqol - bref improved fit over the one - factor model ( p < 0.001 ) . overall , model fit was good : bollen 's incremental fit index ( ifi ) = 0.940 , comparative fit index ( cfi ) = 0.939 , bentler - bonett normed fit index ( nfi ) = 0.933 and the factor loadings for each of the subscales ranged from 0.48 to 1.33 . 1 indicates , the whoqol was one - dimensional at baseline and at exit in that the observed first component was always smaller than that of generated from random data . the explorative factor analysis , parallel factor , in conjunction with the confirmatory factor analysis , meet the assumption of a general whoqol - bref dimension underlying each scale . scree plot of the whoqol - bref at baseline and exit with randomly generated scree ( parallel analysis table 1 demonstrates five parameter estimates / items for all the items of the subscales of the whoqol bref one slope ( a ) , and four threshold separating the five response categories ( b0 , b1 , b2 , and b3 ) . irt parameter estimates for the scales of the 26-item whoqol bref -is the discrimination parameters -is the difficulty parameter in irt , these values of a can range from 0 to around 3 . they represent how quickly an item 's scores change as a function of changes in the latent trait . like factor loadings in a cfa , they capture how closely an item represents the latent trait being measured . as shown in this table , with the exception of item 15 , values of a for all items were large , although some are higher than others . based on baker 's ( 23 ) guidelines , fifteen items have moderate discrimination ( 3 , 4 , 7 , 1114 , 16 , 2026 ) , four items have high discrimination ( 6 , 9 , 18 , 19 ) , two items have very high discrimination ( 2 , 17 ) , and three items have perfect discrimination ( 5 , 8 , 10 ) . to get a sense of what the discrimination values mean , we can view the category response curves ( crc ) , which display how the score probabilities vary as a function of the latent curiosity trait . for the sake of illustration , fig . 2 presents the crcs for all items that differ in their discrimination values . the crcs depict the probability that someone will respond to the item with a 1 , 2 , 3 , 4 , or 5 . the probability level is along the y - axis , and the level of trait quality of life , expressed as a standard normal distribution ( m=0 , sd=1 ) is along the x-axis.the different discrimination values are evident in the peaks and overlaps of the probability curves . illustration of category response and item response functions , and test information function ( continuous lines ) and standard error curves for the four scales of the quality of life . for the items 2 , 5 , 8 , 9 , 17 and 10 , which have a higher discrimination values , the response probabilities have higher peaks and have relatively less overlap . each scale value ( 1 through 5 ) has a region where its absolute probability is at least 50% , indicating that there are trait levels where that response is more probable than the other four options combined . for other items , for the middle three options ( 24 ) , the response curves are never higher than 0.50 . each item has five possible responses , so there are four response thresholds depicted as b1 , b2 , b3 , and b4 . in irt , these thresholds represent the trait levels at which someone has a 50% chance of scoring at or above a scale response . the value for b1 , the threshold between a response of 1 and a response of 2 , is -3.16 . this means that someone with a trait score of -3.16 , a pretty low level , has at least a 50% chance of responding to the item with a 2 , 3 , 4 , or 5 . conversely stated , a response of 1 is the most likely response for people with a quality of life less than -3.16 . the value for b2 , the threshold between the scores of 2 and 3 , is -2.02 . therefore , those with a quality of life score of -2.02 have at least a 50% chance of responding with a 3 , 4 , or 5 . on the whole the last threshold , b4 , is 0.84 , which is only around .12 sd above the mean . this means that a student with a quality of life greater than .84 has at least a 50% chance of responding with a 5 , the highest possible scale score . the difficulty thresholds are related to the frequency with which people chose different response options . item 25 , for example , has very high b4 threshold , and relatively few people responded with a 5 to the item . conversely , item 3 has very low b1 threshold , and relatively few people responded with a 1 to the item . for a self - report scale that measures individual differences , it is desirable for the items to offer information about a broad range of the trait . for this reason , some items should be   easier  and others should be   harder .  an example of a relatively easy item is item 3-its lowest threshold is quite low , and only 1.1% of the sample responded with a 1 to it . only people who are very low in quality of life will respond with low scores to this item . a relatively harder item is item 15 : its highest threshold is 4.66 , so only people who are very high in quality of life will respond with a five . nevertheless , there is not much between - item variation in the difficulty ranges . each item covers a good range of the trait , but the items as a group tend to be centered at the trait 's midpoint . moreover , table 1 shows the threshold parameters ( b1 , b2 , b3 and b4 ) for all the personal items . as it is shown in this table , the b parameter values made noticeable increases in the level of the latent trait at each subsequent response dichotomy . also , the trait values for b1 , b2 and b3 were somewhat evenly spaced with all values below the mean trait level . for all items , the trait values for b4 were only slightly above the mean trait level . table 3 demonstrates the item information function values of the twenty six items in the whoqol bref scale . information for the items in the four scales of the spiritual well - being questionnaire as shown in this table , with the exception of item on 10 , the information values of all the items were quite low at all trait levels . figure 4 displays the test information function for the 4 quality of life scales . as can be seen in these plots , with the exception of items 10 , this indicates that the overall degree of measurement precision for these items is also relatively low . specifically , the items are less precise for measuring individuals with theta levels falling above 1.00 ( e.g. , 3 item ) and below-1(e.g . , 21 item ) . the test information functions ( tif ) provides information on the reliability of the whoqol - bref across the range of latent  trait scores and is computed via a combination of location of the item and discrimination parameters . as noted by neal and colleagues ( 24 ) , when the total information curve is generally peaked , it indicates the highest degree of reliability the scale has at that level of the underlying latent trait score . as shown in fig.3 , the total information curve indicates that the whoqol bref has relatively moderate reliability . note that test information functions for the scale are relatively flat in the low range of  continuum . it does not have distinct peaks , but generally provides most information for  levels between zero and -2 ( measured in standard deviations ) . test information functions for whoqol bref scale appears to be the most evenly spread out across whole range of  continuum . indeed , this scale measures respondents with different levels of quality of life , from low to moderate , with almost equal precision . however , precision of the scale decreases sharply , while standard error of measurement increases sharply when respondents with high quality of life are measured . additional reliability and validation analyses of the whoqol bref . additional analyses focused on examining the reliability and validity of the refined whoqol bref via classical measurement techniques . for these analyses , classical test theory ( ctt ) statistics were conducted for the original 26-item whoqol bref . the cronbach 's alpha values for physical health , psychological health , social relationships and environmental health were 0.65 , 0.77 , 0.52 and 0.79 , respectively . the mean item - to - total correlations were 0.76 , 0.73 , 0.62 and 0.78 for physical health , psychological health , social relationships and environmental health , respectively . for each whoqol - bref , taken together , these findings support the unidimensionality of the four scales and the local independence of the items in each scale . the main purpose of this study was to evaluate psychometric properties of whoqol - bref , in order to determine how useful the instrument is for research , training and development , self - evaluation , self - improvement , promotion and compensation purposes . current psychometric evaluation of the whoqol - bref has been limited to classical test theory ( ctt ) techniques . in recent years , irt methods have been used to develop measurement tools for health status assessment , for example , to construct instruments , score scales , or to validate tests . methods from irt , however , offer several advantages in comparison to methods from ctt such as providing information on the performance of individual scale items and determining an instrument 's reliability across the underlying trait that is purported to measure . recently , these methods have been used to refine measures of health problems ( 24 , 25 ) . data from the whoqol - bref were analyzed using f. samejima 's graded response model . results show that the model fits well and is suitable for the analysis of the questionnaire . the findings for the discrimination parameters of the items showed that with the exception of item 15 , 18 , 24 and 26 , the remainder of all items can discriminate adequately well for low levels of subscales of whoqol - bref , although this ability varies across items . more specifically , the items on 2 , 5 , 8 , 6 , 9 , 17 and10 can discriminate equally well and better than the other items ( 3 , 4 , 7 , 1114 , 16 , 1826 ) . one possible explanation for this finding is that questions with reverse coding ( e.g. item 3 , 4 and26 ) have poorer discriminatory power than un - recoded items . used item - total correlation and irt models to test roskam 's conjecture and found inconsistent effects of wording and item . another study conducted by herche and engelland also found that the use of reversed - polarity items led to some problems . a mixed use of positively and negatively worded items in the same scale can adversely affect measurement consistency . furthermore , one explanation for this finding is that some items ( 3 , 4 , 6 , 9 , 1114 , 26 ) were so specific that they were more suitable for assessing a particular subgroup rather than a general population , and as a consequence these items also provided little information when assessing the qol of a relatively healthy population in this case . in other words , general questions ( 1 , 2 , 17 ) overall performed better than object - specific items . overall , irt analysis shows that whoqol - bref measure appears to be a moderately reliable instrument , better suited for identifying moderate quality of life levels . there are some caveats that the reader should be aware of when interpreting these results . this results from either improved estimation of the s or improved estimation of the shape of the  distribution . in addition , increasing the number of examinees can somewhat improve the estimation of  through improved estimation of the item parameters ( 28 ) . in other words , for polychromous models , the number of examinees per category can make a difference in the accuracy of the category parameter estimation , and the thresholds are more accurately estimated for middle categories than for extreme categories . the category parameters are also estimated better when examinees are distributed more evenly across categories ( 28 ) . better - quality items will be more discriminating and more useful for estimating . the accuracy of the item parameter estimates obviously has some impact on  estimation as well , so increasing the examinee sample size and thus increasing the item parameter accuracy can increase the precision of  estimation . therefore , whoqol - bref scales could be improved by removing some of the redundant items with low discrimination power ( e.g. 24 ) and by adding new , and more  difficult items located in the upper part of the quality of life ability (  ) continuum in university population . thus , the items with low reliability may need to be revised to improve their reliability . indeed , the overall results of this study are supportive of its psychometric properties , so has been the result of previous study ( 26 ) . this study also was in accordance with the work of lin & yao ( 27 ) who reported that a more precise and valid measure of the qol can be constructed using the irt approach . it is important not only to develop a comprehensive but also short and easily administered qol instrument , which will have a significant impact for clinical or research purposes . in conclusion , this study has suggested that the use of irt procedures can provide valuable additional psychometric information . it is well documented that good ctt- based psychometric properties for a measure do not necessarily mean that it would have good irt - based psychometric properties . this study has also demonstrated how irt can be used to revise the existing measures . it is hoped that this study could be able to show the value of using irt to evaluate the psychometric properties of measures , test development and revision , and that it would encourage other researchers to use irt approaches for similar purposes . researchers should keep in mind that irt analyses are affected by response tendencies and social desirability . therefore , additional research is needed on the whoqol - bref , especially efforts designed to increase measurement precision at the high - end of the scale , as well as studies of differential item functioning ( dif ) and computer adaptive testing ( cat ) . the reliance on cross - sectional assessment strategies and college student samples raise questions about the generalizability of the findings . we are hopeful that the ongoing result will be examined in other samples with different age groups and different socio - cultural backgrounds so it will not be limited to university students .
objectivethis study has used item response theory ( irt ) to examine the psychometric properties of health - related quality-of-life.methodthis investigation is a descriptive- analytic study . 
 subjects were 370 undergraduate students of nursing and midwifery who were selected from tabriz university of medical sciences . 
 all participants were asked to complete the farsi version of whoqol - bref . 
 samejima 's graded response model was used for the analyses.resultsthe results revealed that the discrimination parameters for all items in the four scales were low to moderate . 
 the threshold parameters showed adequate representation of the relevant traits from low to the mean trait level . with the exception of 15 , 18 , 24 and 26 items , all other items showed low item information function values , and thus relatively high reliability from low trait levels to moderate levels.conclusionsthe results of this study indicate that although there was general support for the psychometric properties of the whoqol - bref from an irt perspective , this measure can be further improved . 
 irt analyses provided useful measurement information and demonstrated to be a better methodological approach for enhancing our knowledge of the functionality of whoqol - bref .