- Open Access
Validation of the Rasch-based Depression Screening in a large scale German general population sample
© Forkmann et al; licensee BioMed Central Ltd. 2010
- Received: 4 May 2010
- Accepted: 21 September 2010
- Published: 21 September 2010
The study aimed at presenting normative data for both parallel forms of the "Rasch-based Depression Screening (DESC)", to examine its Rasch model conformity and convergent and divergent validity based on a representative sample of the German general population.
The sample was selected with the assistance of a demographic consulting company applying a face to face interview (N = 2509; mean age = 49.4, SD = 18.2; 55.8% women). Adherence to Rasch model assumptions was determined with analysis of Rasch model fit (infit and outfit), unidimensionality, local independence (principal component factor analysis of the residuals, PCFAR) and differential item functioning (DIF) with regard to participants' age and gender. Norm values were calculated. Convergent and divergent validity was determined through intercorrelations with the depression and anxiety subscales of the Hospital Anxiety and Depression Scale (HADS-D and HADS-A).
Fit statistics were below critical values (< 1.3). There were no signs of DIF. The PCFAR revealed that the Rasch dimension "depression" explained 68.5% (DESC-I) and 69.3% (DESC-II) of the variance, respectively which suggests unidimensionality and local independence of the DESC. Correlations with HADS-D were r DESC-I = .61 and r DESC-II = .60, whereas correlations with HADS-A were r DESC-I = .62 and r DESC-II = .60.
This study provided further support for the psychometric quality of the DESC. Both forms of the DESC adhered to Rasch model assumptions and showed intercorrelations with HADS subscales that are in line with the literature. The presented normative data offer important advancements for the interpretation of the questionnaire scores and enhance its usefulness for clinical and research applications.
- Differential Item Functioning
- Item Response Theory
- Item Difficulty
- Symptom Burden
- Item Bank
Screening for depression is an important diagnostic task in many clinical settings. Several established screening instruments are available for this purpose like the Beck Depression Inventory [BDI; 1], the Patient Health Questionnaire 9 [PHQ-9; 2], or the Hospital Anxiety and Depression Scale [HADS; 3,4]. Most of the established instruments were originally developed on the basis of classical test theory (CTT) and many studies reported excellent reliability and validity for these instruments when relying upon CTT assumptions [e.g., 5,6].
However, in the last years it was demonstrated that diagnostic instruments could benefit substantially from modern statistical approaches like models of item response theory (IRT), e.g., the Rasch model. The Rasch model is one of the IRT models that holds some particularly beneficial attributes, e.g., interval scale level of model parameters, sample free test calibration, and item free person measurement [for an introduction to Rasch analysis, see 7,8]. Applying IRT techniques, a slightly more differentiated picture of the psychometric properties of the established screening instruments for depression emerged. For instance, by using IRT modeling it was shown that unidimensionality - an important aspect of test theory - cannot be taken for granted for some instruments [9, 10]. Furthermore it was shown that instruments containing items related to somatic symptoms could lead to severe problems when assessing patients with comorbid somatic diseases. If patients suffering from a severe somatic illness reported somatic symptoms in a depression questionnaire those symptoms may be ascribed to the somatic ailment or a depressive episode [11–13]. This may lead to artificially increased depression scores. Moreover, using IRT methods it was shown that established questionnaires could be shortened without loss of information . Generally, in many studies applying IRT techniques, sound psychometric characteristics of a depression screening instrument could only be found if at least some items were removed from the scale. The question, which items had to be removed largely depended on the sample investigated [e.g., 13,15-17]. However, sample dependent psychometric characteristics of screening instruments may aggravate the comparison of results across different samples or studies.
The Rasch-based De pression Sc reening (DESC) is one of the first instruments that were originally developed using Rasch analysis. Its development was motivated by two aspects. First, given the evidence for sample-dependency of psychometric characteristics of many screening instruments for depression when applying IRT modeling, the first aim was to use Rasch analysis to originally develop a new instrument with stable psychometric characteristics across a diversity of different clinical and non-clinical samples. Second, as prior studies have shown that using questionnaires of mood repeatedly at short intervals produces artificial alteration of sum scores [18, 19] an instrument that provides two parallel forms was lacking. Parallel forms are beneficial for retest applications in longitudinal designs, e.g., monitoring symptom change across treatment.
The DESC has already been shown to fit the Rasch model in various patient samples, e.g., cardiologic, otorhinolaryngologic, neurologic patients or patients with mental illnesses [20, 21]. So, research up to now suggests that the DESC is a psychometrically sound and concise screening instrument consisting of two parallel forms which measures depression severity across a broad range of depression severity with high test accuracy.
However, despite the development of the DESC is in an advanced stage, population based norms are lacking to date. Population based norms for the DESC would enhance easiness and reliability of diagnostic decisions based on the DESC sum score on a single case basis. It would provide important advancements for the interpretation of the questionnaire scores and enhance its usefulness for clinical and research applications.
The primary aim of the current study was therefore to collect normative data for both forms of the DESC based on a representative sample of the German general population. Prior to determination of norm values, Rasch model conformity of the DESC in this sample was examined. Furthermore, convergent and divergent validity of the DESC with regard to the anxiety and the depression subscale of the Hospital Anxiety and Depression Scale [HADS; 4,22] were determined. Possible applications of the presented normative data are discussed.
N = 2509
44.2% (N = 1109)
55.8% (N = 1400)
< 10 years
10 years of education
> 10 years
Net household income
1251 to 2500€/month
All participants were visited by an interview assistant and informed about the investigation. The interview was based on a structured questionnaire that was filled in by the respondents. An interview assistant waited until the participant completed all questions and offered help if participants did not understand the meaning of the questions or the use of the response scale. The study procedures were in accordance with the declaration of Helsinki and approved by the local ethics committee.
DESC. The Rasch-based Depression Screening [DESC; 20] was developed on the basis of a calibrated Rasch-homogeneous item bank [see 23 for details on the construction process]. For the development of the DESC, items of the item bank were selected if they showed an excellent fit to the Rasch model. Furthermore, selected items should capture a broad range of depression severity similar to the range covered by the whole item bank. Structural equation modelling was applied to evaluate equivalence of the two scales . Using Receiver Operating Characteristics (ROC) curves analysis the optimal cut-off score of both DESC forms was determined to be ≥12 with regard to interview-based diagnosis of a depressive disorder according to ICD-10 . This cut-off score proved to be sensitive and specific. The DESC was developed to assess depression in both patients with mental and somatic illnesses. In the initial development it was found that no items on somatic symptoms could be included to the instrument because these items did not fit the model and violated the unidimensionality assumption of the scale .
Item characteristics of the Rasch-based Depression Screening I (DESC-I) and the Rasch-based Depression Screening II (DESC-II)
δ i *
loss of joy
life is a burden
life is a failure
be no good
loss of interest
HADS. The Hospital Anxiety and Depression Scale [HADS; 3,4,25] refers to the last week and consists of 14 items which are Likert scaled from 0 to 3 with changing polarity. Seven items each constitute the anxiety and the depression subscales. A cut off score of ≥ 8 is recommended to identify persons suffering from a depressive disorder according to ICD-10 . The HADS was used to calculate measures of convergent and divergent validity of the DESC. The HADS was chosen to validate the DESC because it was originally developed for depression screening in patients with somatic diseases, which is also one the main fields of application for the DESC. Furthermore, it provides screening information on depression and anxiety symptoms, so that both convergent and divergent validity could be examined simultaneously.
Further material. All participants completed a demographic data sheet.
Data analysis was conducted in two steps. In the first step, it was examined whether the Rasch model holds in the representative German general population sample. In the second step, based on these data norm values and measures of convergent and divergent validity were determined.
Step 1: Rasch analysis
The Rasch model conceptualizes the probability that a person will endorse an item as a logistic function of the difference between the person's level of, in this case, depression (θ, also referred to as the latent trait score or person measure) and the level of depression expressed by the item (δ i ) . Because the Rasch model was originally developed for intelligence and attainment tests, δ i is also often referred to as "item difficulty" . For self-report instruments, this term can be "translated" as probability expressed in logits to endorse a high category of an item. For "difficult" items this probability would be lower than for "easy" items, relative to the individual person measure. In this step, all analyses were performed applying an extension of the Rasch Model, the Partial Credit Model [PCM; 28]. The PCM allows response categories to vary across items. This model was chosen because it was shown to be more appropriate to use the PCM than the competing Rating Scale Model in the original development of the DESC . To ensure comparability of the results presented here with the original development sample of the DESC, item difficulty estimates δ i and thresholds were anchored on the original calibration sample reported in Forkmann et al. .
Separation and reliability
The item and person separation indices estimate the spread or separation of persons and items on the measured variable relative to measurement error. Items must be sufficiently well separated in terms of item difficulty in order to identify the direction and meaning of the latent scale . A clinically useful set of items should define at least three strata of patients and items (e.g., high, moderate, and low levels of symptom burden), which are reflected in a separation index of 2.0 and an associated separation reliability of. 80 [8, 29].
Rasch model fit
Infit and outfit are mean square residual statistics of model fit discrepancy with an expectation of 1.0 and a range from 0 to infinity. Infit and outfit statistics reflect slightly different approaches to assessing the fit of an item: The infit statistic gives relatively more weight to the answers of those persons closer to the item measure, whereas the outfit statistic is not weighted and therefore more sensitive to the influence of "outlying", i.e. more extreme responses. Values ≤ 1.3 indicate good fit .
Unidimensionality and local independence
Unidimensionality and local independence are two important interrelated assumptions of Item Response Theory. Unidimensionality means that only one single latent dimension (e.g., depression) accounts for the common variance in the data. Evidence of essential unidimensionality provides support for the assumption of local independence because if all items measure the same underlying construct, this construct accounts for any relationships among items, and other relationships among items are unlikely . Thus, local independence means that when controlling for the major latent dimension no substantial intercorrelations between the items shall remain. A principal component factor analysis of the residuals (PCFAR) was performed [31, 32]. Since uniform criteria have yet to be established for when a potential additional dimension would have to be considered, results were interpreted according to the recommendations of Linacre : > 60% of variance explained by the Rasch dimension and ≤ 5% explained by the greatest potential additional dimension was considered as good. Additionally, an eigenvalue ≤ 3 indicates that the potential second dimension has only marginal explanatory power. This result allows for ignoring further components .
Evaluation of Differential Item Functioning (DIF)
Differential item functioning (DIF) investigates the items in an instrument for signs of interactions with sample characteristics. DIF analyses were performed for gender and age for three reasons: Firstly, many studies showed that prevalence of depression depends on age and gender [34, 35]. Thus, DIF due to these variables might be suspected. Secondly, prior studies analysing self-report instruments for depression found DIF related to age [36–38] and DIF related to gender . Furthermore, we considered it most important to investigate whether the DESC can be used for both genders and all age groups without different norms because this would imply a notable practical advantage for clinical practice. Therefore, Item difficulty measures δ i were computed for each class of subjects (e.g., men vs. women) to be contrasted. A two-sided t-test was then performed pair wise comparing item difficulty measures for subject classes (α ≤ 0.01). In accordance to the studies reporting the initial development of the DESC [20, 23] and following Linacre's recommendations to interpret these t-tests conservatively, additionally to the significant t-test, a DIF contrast (i.e., DIF measure for subject class 1 minus subject class 2) of | > .5| was considered substantial .
Step 2: Determination of DESC norm values and measures of convergent and divergent validity
After determination of adherence to Rasch model assumptions norm values were calculated separately for DESC-I and DESC-II according to the following routine. First, based on the individual raw sum scores each person's latent trait score θ was calculated. Then, trait scores θ were transformed linearly into percentiles, z-values (mean = 0, SD = 1) and T-values (mean = 50, SD = 10). Afterwards, correlations of both DESC forms with the depression and the anxiety scale of the HADS were calculated as measures for convergent and divergent validity. Possible applications of these normative data for the assessment of change in clinical diagnostics are exemplified in the discussion section.
All analyses were conducted using WINSTEPS 3.60.1 and SPSS 17.
Step 1: Rasch analysis
Separation and reliability
Item separation for DESC-I (11.15) and DESC-II (11.11) was very good as well as item reliability (DESC-I = .99; DESC-II = .99). Person separation (DESC-I = 1.51; DESC-II = 1.75) and person reliability (DESC-I = .69; DESC-II = .75) failed slightly the critical values. Cronbach's α was high with .92 for DESC-I and .93 for DESC-II, respectively.
Rasch model fit
All items of both DESC-I and DESC-II adhered to the infit and outfit criteria of < 1.3 indicating very good Rasch model fit. See table 2 for details.
Unidimensionality and local independence
To evaluate unidimensionality and local independence the residual correlation matrix was examined. A principal component factor analysis of the residuals (PCFAR) revealed that the Rasch dimension "depression" explained 68.5% of the variance (eigenvalue 21.8) in DESC-I and 69.3% of the variance (eigenvalue 22.6) in DESC-II. The biggest potential secondary dimension explained 5.0% of the variance (eigenvalue 1.6) both in DESC-I and DESC-II. This result is in line with the assumptions of both unidimensionality and local independence of the data, since the recommendations of Linacre  are fulfilled.
Evaluation of Differential Item Functioning (DIF)
There were no signs of DIF due to age or gender for both DESC-I and DESC-II. Thus, sum scores of both forms of DESC may be interpreted independently from the respondents' age or gender.
Step 2: Determination of DESC norm values and measures of convergent and divergent validity
Norm values for DESC-I
Norm values for DESC-II
The population mean of DESC-I was M = 3.9 (SD = 5.4) and of DESC-II was M = 4.0 (SD = 5.6). When applying the proposed cut-off score of 12 , DESC-I would classify 10.0% of the representative sample as being depressed, while DESC-II classifies 10.8% to be depressed. The concordance of both classifications according to the coefficient κ for nominal data is κ = .73. The depression subscale of the HADS would classify 24.5% of the sample as depressed.
The parallel test reliability of DESC-I and -II was r = .93 (p < .01). The correlation with the depression subscale of the HADS was moderate for DESC-I (r = .61; p < .01) as well as for DESC-II (r = .60). The correlation with the anxiety subscale of the HADS was r = .62 for DESC-I and r = .60 for DESC-II.
This study aimed at validating the DESC in a representative sample of the German general population and at providing normative data and measures of convergent and divergent validity of both forms of the instrument.
Overall, both forms of the DESC adhered to Rasch model assumptions. We found very good Rasch model fit according to infit and outfit statistics, strong evidence for unidimensionality and local independence, and no signs of differential item functioning. Keeping in mind that the DESC's validity in clinical samples has already been shown [20, 40], these results additionally suggest, that the DESC appears to be a psychometrically sound instrument for screening for depression in the general population. Furthermore, the high parallel test reliability could be replicated indicating that the DESC can be applied as true parallel versions of the same inventory in retest applications.
The fraction of the sample that was classified as depressed when applying the proposed cut-off score of the two DESC parallel forms roughly corresponds to the German prevalence rates reported in the literature [see e.g., 41]. While sound criteria for external validity are lacking in the current study, this concordance may be cautiously interpreted as suggesting validity. Furthermore, prior studies in patient samples indicated good external validity of the DESC [see e.g., 20].
The reported values for convergent and divergent validity were moderate. Anxiety and depression are known to be substantially correlated so that moderate positive correlations of self-report instruments for depression with measures of anxiety are a common phenomenon. Thus, the moderate positive correlation with the anxiety subscale of the HADS is in concordance with prior literature . Furthermore, the correlation between the depression and anxiety subscales of the HADS itself was comparably high (r = .68) so that the moderate positive correlation of the DESC with anxiety does not flaw its validity.
We expected high convergent validity with the depression subscale of the HADS. However, the revealed correlation was only moderate, too. In order to appraise the significance of this result for the standing of the DESC compared to the established self-report instruments for depression, like the HADS , the Beck Depression Inventory [BDI; 1], or the Center for Epidemiologic Studies Depression Scale [CES-D; 43], it has to be taken into account that moderate convergent validity with other self-report instruments for depression has been reported for most other depression questionnaires, too. For example, both Bonilla and colleagues  and Kojima and colleagues  reported a correlation between BDI and CES-D of r = .69. Cameron and colleagues  found a correlation between the HADS and the Patient Health Questionnaire [PHQ-9; 2] of r = .68. Thus, the correlation between DESC and the depression subscale of the HADS is in concordance with recent findings from the literature. Furthermore, HADS and DESC might emphasize different aspects of depression. For example, in contrast to the HADS both forms of the DESC contain an item about suicidal ideation and behaviour which could at least partly account for the surprising results. Moreover, DESC (2 weeks) and HADS (1 week) refer to different timeframes and the HADS contains items with changing polarity whereas the DESC does not. Theses factors might add to the relatively low correlation of the scales. Above, in our sample the HADS classified more then twice as many persons as depressed as the DESC. Since the DESC classifications roughly correspond to the prevalence of depression reported in the literature this result might be interpreted as indicating that the HADS tends to produce "false positives" in the general population - a fact that has already been discussed for depression screening with the HADS in other samples [e.g., 26]. Nevertheless, future research should further investigate the construct validity of the DESC to substantiate the present findings.
Possible applications of the presented normative data
The DESC was shown to be a reliable and valid instrument in prior studies [20, 40]. Its sum-score can be interpreted as valid quantitative estimate of a person's depressive symptom burden, and it provides a sensitive and specific cut-off score which aids in deciding whether a depressive disorder is likely to be present. However, the normative data presented in the current study further facilitate the clinical utilization of the instrument. The provided T- and Z-scores allow for comparing DESC sumscores with the distribution of sumscores in the general population. Thus, clinicians may now come to a rapid binary decision about the clinical status of a patient by applying the cut-off score. But above, a more fine graded evaluation of the patient's state is possible by comparing his scores with the distribution in the general population. This may be beneficial for clinical application, particularly in repeated assessments. The issue how to determine significant change across treatment has been subject to intense and vivid discourse in psychotherapy research in the past [see 47 for a review]. Important recommendations how to deal with this problem have been made by e.g. Jacobson and Truax . Amongst other important suggestions, they point out that a central aspect of the evaluation of clinical significant change is the returning of the patient's score to the range of the mean plus one standard deviation of the general population distribution. This refers to the "cutoff point b" as presented by the authors [see 47 for details]. With the normative data presented here, clinicians now can follow this recommendation when using the DESC.
Taken together, the present study provides further evidence for the psychometric quality of the DESC and opens new opportunities for sumscore interpretation through the presentation of normative data. The major strengths of the instrument can be expected in retest applications in both clinical and nonclinical samples. We conclude that the instrument can be useful in dealing with the central challenges of clinical assessment: (1) to measure a patient's symptom burden quantitatively, (2) to decide, whether this measurement indicates the presence of a depressive disorder, and (3) to judge whether symptom burden changes in the course of treatment.
- Beck AT, Steer RA: Beck Depression Inventory. San Antonio: The Psychological Corperation Inc; 1987.Google Scholar
- Kroenke K, Spitzer RL, Williams JB: The PHQ-9: validity of a brief depression severity measure. J Gen Intern Med 2001, 16: 606–613. 10.1046/j.1525-1497.2001.016009606.xPubMed CentralPubMedView ArticleGoogle Scholar
- Herrmann C, Buss U, Snaith RP: Hospital Anxiety and Depression Scale - Deutsche Version (HADS-D). Manual. Bern: Hans Huber; 1995.Google Scholar
- Zigmond AS, Snaith RP: The Hospital Anxiety and Depression Scale. Acta Psychiatr Scand 1983, 67: 361–370. 10.1111/j.1600-0447.1983.tb09716.xPubMedView ArticleGoogle Scholar
- Löwe B, Spitzer RL, Grafe K, Kroenke K, Quenter A, Zipfel S, et al.: Comparative validity of three screening questionnaires for DSM-IV depressive disorders and physicians' diagnoses. J Affect Disord 2004, 78: 131–140. 10.1016/S0165-0327(02)00237-9PubMedView ArticleGoogle Scholar
- Thombs BD, Magyar-Russell G, Bass EB, Stewart KJ, Tsilidis KK, Bush DE, et al.: Performance characteristics of depression screening instruments in survivors of acute myocardial infarction: review of the evidence. Psychosomatics 2007, 48: 185–194. 10.1176/appi.psy.48.3.185PubMedView ArticleGoogle Scholar
- Bond TG, Fox CM: Applying the Rasch model: Fundamental measurement in the human sciences. Mahwah, New Jersey: Lawrence Erlbaum; 2001.Google Scholar
- Gauggel S, Boecker M, Heinemann AW, Lämmler G, Borchelt M, Steinhagen-Thiessen E: Patient-Staff Agreement on Barthel Index Scores at Admission and Discharge in a Sample of Elderly Stroke Patients. Rehabil Psychol 2004, 49: 21–27. 10.1037/0090-55184.108.40.206View ArticleGoogle Scholar
- de Bonis M, Lebeaux MO, de Boeck P, Simon M, Pichot P: Measuring the severity of depression through a self-report inventory. A comparison of logistic, factorial and implicit models. J Affect Disord 1991, 22: 55–64. 10.1016/0165-0327(91)90084-6PubMedView ArticleGoogle Scholar
- Licht RW, Qvitzau S, Allerup P, Bech P: Validation of the Bech-Rafaelsen Melancholia Scale and the Hamilton Depresson Scale in patients with major depression; is the total score a valid measure of illness severity? Acta Psychiatr Scand 2005, 111: 144–149. 10.1111/j.1600-0447.2004.00440.xPubMedView ArticleGoogle Scholar
- Alexopoulos GS, Borson S, Cuthbert BN, Devanand DP, Mulsant BH, Olin JT, et al.: Assessment of late life depression. Biol Psychiatry 2002, 52: 164–174. 10.1016/S0006-3223(02)01381-1PubMedView ArticleGoogle Scholar
- Gauggel S, Schmidt A, Didié M: Körperliche Beschwerden und deren Einfluss auf die Erfassung depressiver Störungen bei jüngeren und älteren Menschen. Z Gerontopsychol Gerontopsychiatr 1994, 7: 203–210.Google Scholar
- Siegert RJ, Tennant A, Turner-Stokes L: Rasch analysis of the Beck Depression Inventory-II in a neurological rehabilitation sample. Disabil Rehabil 2010, 32: 8–17. 10.3109/09638280902971398PubMedView ArticleGoogle Scholar
- Tang WK, Wong E, Chiu HF, Lum CM, Ungvari GS: The Geriatric Depression Scale should be shortened: results of Rasch analysis. Int J Geriatr Psychiatry 2005, 20: 783–789. 10.1002/gps.1360PubMedView ArticleGoogle Scholar
- Cole JC, Smith TL, Rabin AS, Kaufmann AS: Development and Validation of a Rasch-Derived CES-D Short Form. Psychol Assess 2004, 16: 360–372. 10.1037/1040-35220.127.116.110PubMedView ArticleGoogle Scholar
- Forjaz MJ, Rodriguez-Blazquez C, Martinez-Martin P: Rasch analysis of the hospital anxiety and depression scale in Parkinson's disease. Mov Disord 2009, 24: 526–532. 10.1002/mds.22409PubMedView ArticleGoogle Scholar
- Kendel F, Wirtz M, Dunkel A, Lehmkuhl E, Hetzer R, Regitz-Zagrosek V: Screening for depression: Rasch analysis of the dimensional structure of the PHQ-9 and the HADS-D. J Affect Disord 2010, 122: 241–246. 10.1016/j.jad.2009.07.004PubMedView ArticleGoogle Scholar
- Choquette KA, Hesselbrock MN: Effects of retesting with the Beck and Zung depression scales in alcoholics. Alcohol Alcohol 1987, 22: 277–283.PubMedGoogle Scholar
- Sharpe JP, Gilbert DG: Effects of repeated administration of the Beck Depression Inventory and other measures of negative mood states. Pers Individ Diff 1998, 24: 457–463. 10.1016/S0191-8869(97)00193-1View ArticleGoogle Scholar
- Forkmann T, Boecker M, Wirtz M, Eberle N, Westhofen M, Schauerte P, et al.: Development and validation of the Rasch-based depression screening (DESC) using Rasch analysis and structural equation modelling. J Behav Ther Exp Psychiatry 2009, 40: 468–478. 10.1016/j.jbtep.2009.06.003PubMedView ArticleGoogle Scholar
- Böcker M, Forkmann T, Norra C, Wirtz M, Eberle N, Hesse M, et al.: Validierung des Rasch-basierten Depressionsscreenings (DESC) an einer neurologischen Stichprobe. Z Neuropsychol 2009, 20: 227–264. Abstract 10.1024/1016-264X.20.3.227View ArticleGoogle Scholar
- Hinz A, Schwarz R: [Anxiety and depression in the general population: normal values in the Hospital Anxiety and Depression Scale]. Psychother Psychosom Med Psychol 2001, 51: 193–200. 10.1055/s-2001-13279PubMedView ArticleGoogle Scholar
- Forkmann T, Boecker M, Norra C, Eberle N, Kircher T, Schauerte P, et al.: Development of an item bank for the assessment of depression in persons with mental illnesses and physical diseases using Rasch analysis. Rehabil Psychol 2009, 54: 186–197. 10.1037/a0015612PubMedView ArticleGoogle Scholar
- World Health Organization: The ICD-10 classification of mental and behavioral disorders: clinical descriptions and diagnostic guidelines. Geneva: World Health Organization; 1992.Google Scholar
- Hinz A, Zweynert U, Kittel J, Igl W, Schwarz R: [Measurement of change with the Hospital Anxiety and Depression Scale (HADS): sensitivity and reliability of change]. Psychother Psychosom Med Psychol 2009, 59: 94–400. 10.1055/s-2008-1067578View ArticleGoogle Scholar
- Olsson I, Mykletun A, Dahl AA: The Hospital Anxiety and Depression Rating Scale: a cross-sectional study of psychometrics and case finding abilities in general practice. BMC Psychiatry 2005, 5: 46. 10.1186/1471-244X-5-46PubMed CentralPubMedView ArticleGoogle Scholar
- Rasch G: Probabilistic models for some intelligence and attainment tests. Chicago: University of Chicago Press; 1960.Google Scholar
- Masters GN: A Rasch model for partial credit scoring. Psychometrika 1982, 47: 149–174. 10.1007/BF02296272View ArticleGoogle Scholar
- Wright BD, Stone MH: Five Steps to Science: Observing, Scoring, Measuring, Analyzing, and Applying. Rasch Meas Trans 2003, 17: 912–913.Google Scholar
- Embretson SE, Reise SP: Item response theory for psychologists. Mahwah, NJ: Erlbaum; 2000.Google Scholar
- Linacre JM: Structure in Rasch residuals: Why principal component analysis (PCA). Rasch Meas Trans 1998, 12: 636.Google Scholar
- Smith RM, Miao CY: Assessing unidimensionality for Rasch measurement. In Objective Measurement. Edited by: Wilson M. Norwood, NJ: Ablex Publishing Corporation; 1994:316–327.Google Scholar
- Linacre JM: A User's Guide to WINSTEPS. Chicago; 2006.Google Scholar
- Gottlieb SS, Khatta M, Friedmann E, Einbinder L, Katzen S, Baker B, et al.: The influence of age, gender, and race on the prevalence of depression in heart failure patients. J Am Coll Cardiol 2004, 43: 1542–1549. 10.1016/j.jacc.2003.10.064PubMedView ArticleGoogle Scholar
- Wittchen HU, Jacobi F: Size and burden of mental disorders in Europe--a critical review and appraisal of 27 studies. Eur Neuropsychopharmacol 2005, 15: 357–376. 10.1016/j.euroneuro.2005.04.012PubMedView ArticleGoogle Scholar
- Balsis S, Cully JA: Comparing depression diagnostic symptoms across younger and older adults. Aging Ment Health 2008, 12: 800–806. 10.1080/13607860802428000PubMedView ArticleGoogle Scholar
- Fliege H, Becker J, Walter oB, Bjorner JB, Klapp BF, Rose M: Development of a computer-adaptive test for depression (D-CAT). Qual Life Res 2005, 14: 2277–2291. 10.1007/s11136-005-6651-9PubMedView ArticleGoogle Scholar
- Shea TL, Tennant A, Pallant JF: Rasch model analysis of the Depression, Anxiety and Stress Scales (DASS). BMC Psychiatry 2009, 9: 21. 10.1186/1471-244X-9-21PubMed CentralPubMedView ArticleGoogle Scholar
- Broekman BF, Nyunt SZ, Niti M, Jin AZ, Ko SM, Kumar R, et al.: Differential item functioning of the Geriatric Depression Scale in an Asian population. J Affect Disord 2008, 108: 285–290. 10.1016/j.jad.2007.10.005PubMedView ArticleGoogle Scholar
- Forkmann T, Norra C, Wirtz M, Gauggel S, Boecker M: Psychometric Evaluation of the Rasch-Based Depression Screening in Patients With Neurologic Disorders. Arch Phys Med Rehabil 2010, 91: 1188–1193. 10.1016/j.apmr.2010.04.021PubMedView ArticleGoogle Scholar
- Jacobi F, Wittchen HU, Holting C, Hofler M, Pfister H, Muller N, et al.: Prevalence, co-morbidity and correlates of mental disorders in the general population: results from the German Health Interview and Examination Survey (GHS). Psychol Med 2004, 34: 597–611. 10.1017/S0033291703001399PubMedView ArticleGoogle Scholar
- Storch EA, Roberti JW, Roth DA: Factor structure, concurrent validity, and internal consistency of the Beck Depression Inventory-Second Edition in a sample of college students. Depress Anxiety 2004, 19: 187–189. 10.1002/da.20002PubMedView ArticleGoogle Scholar
- Radloff LS: The CES-D Scale: a self-report depression scale for research in the general population. Appl Psychol Meas 1977, 1: 385–401. 10.1177/014662167700100306View ArticleGoogle Scholar
- Bonilla J, Bernal G, Santos A, Santos D: A revised Spanish version of the Beck Depression Inventory: psychometric properties with a Puerto Rican sample of college students. J Clin Psychol 2004, 60: 119–130. 10.1002/jclp.10195PubMedView ArticleGoogle Scholar
- Kojima M, Furukawa TA, Takahashi H, Kawai M, Nagaya T, Tokudome S: Cross-cultural validation of the Beck Depression Inventory-II in Japan. Psychiatry Res 2002, 110: 291–299. 10.1016/S0165-1781(02)00106-3PubMedView ArticleGoogle Scholar
- Cameron IM, Crawford JR, Lawton K, Reid IC: Psychometric comparison of PHQ-9 and HADS for measuring depression severity in primary care. Br J Gen Pract 2008, 58: 32–36. 10.3399/bjgp08X263794PubMed CentralPubMedView ArticleGoogle Scholar
- Jacobson NS, Roberts LJ, Berns SB, McGlinchey JB: Methods for defining and determining the clinical significance of treatment effects: description, application, and alternatives. J Consult Clin Psychol 1999, 67: 300–307. 10.1037/0022-006X.67.3.300PubMedView ArticleGoogle Scholar
- Jacobson NS, Truax P: Clinical significance: a statistical approach to defining meaningful change in psychotherapy research. J Consult Clin Psychol 1991, 59: 12–19. 10.1037/0022-006X.59.1.12PubMedView ArticleGoogle Scholar
This article is published under license to BioMed Central Ltd. This is an Open Access article distributed under the terms of the Creative Commons Attribution License (http://creativecommons.org/licenses/by/2.0), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.