- Open Access
The importance of rating scales in measuring patient-reported outcomes
Health and Quality of Life Outcomes volume 10, Article number: 80 (2012)
A critical component that influences the measurement properties of a patient-reported outcome (PRO) instrument is the rating scale. Yet, there is a lack of general consensus regarding optimal rating scale format, including aspects of question structure, the number and the labels of response categories. This study aims to explore the characteristics of rating scales that function well and those that do not, and thereby develop guidelines for formulating rating scales.
Seventeen existing PROs designed to measure vision-related quality of life dimensions were mailed for self-administration, in sets of 10, to patients who were on a waiting list for cataract extraction. These PROs included questions with ratings of difficulty, frequency, severity, and global ratings. Using Rasch analysis, performance of rating scales were assessed by examining hierarchical ordering (indicating categories are distinct from each other and follow a logical transition from lower to higher value), evenness (indicating relative utilization of categories), and range (indicating coverage of the attribute by the rating scale).
The rating scales with complicated question format, a large number of response categories, or unlabelled categories, tended to be dysfunctional. Rating scales with five or fewer response categories tended to be functional. Most of the rating scales measuring difficulty performed well. The rating scales measuring frequency and severity demonstrated hierarchical ordering but the categories lacked even utilization.
Developers of PRO instruments should use a simple question format, fewer (four to five) and labelled response categories.
Patient-reported outcomes (PROs) are the measurement of patients’ perception of the impact of a disease and its treatment(s), which are typically reported via a questionnaire . PROs are increasingly being accepted as the primary endpoints of clinical trials in health research [2–4]. The U.S. Food and Drug Administration (FDA) has also endorsed PROs as key clinical trial endpoints owing to the notion that such clinical trials ultimately guide patient care . Therefore, it is critical that data collected by PROs are accurate and reliable, which is only possible when patients are able to understand the questions asked and select response categories that represent their status. Poorly understood questions, or underutilized rating scale categories can seriously impair the accuracy and reliability of PRO measurements [6–8].
The term rating scale generally refers to the response options that can be selected for a question or statement in a PRO instrument [7, 8]. These are usually a set of categories defined by descriptive labels: rating scale categories. According to the general guidelines, rating scale categories should be presented in a clear progression (categories distinct from each other), should be conceptually exhaustive (no gaps within the range of response choices), and should be appropriate to the question of the latent trait being measured . The performance of rating scale categories is also intimately connected to the format of the question . Therefore, rating scale design should consider aspects of both the question format and the response categories.
The development of appropriate rating scale categories may seem straightforward; however, in the absence of high quality evidence, or consensus for the optimal methods, PRO developers take many different approaches. Perhaps the most debated issue is the optimum number of response categories. Some researchers argue that more reliable and precise measurement can be obtained with more response categories (more than seven) . Whereas, others favour a small number of response categories based on the theory that fewer response options offer minimum respondent confusion and reduce respondent burden . Therefore, PRO developers face a trade-off: achieve finer discrimination through a greater number of response categories versus reducing respondent burden and not exceeding the discrimination capacity of the respondents . However, there are no clear guidelines available to inform this choice. Other contested issues are whether the same rating scale should be applied to all questions measuring an underlying trait, what are the optimal features involved in question formatting and what is the optimal rating scale category labelling.
In order to develop the evidence base for rating scale design, a project was undertaken to assess the rating scale used in 17 existing PRO instruments which were developed to measure the impact of cataract and/or outcomes of cataract surgery. The aim of this study was to use Rasch analysis to identify features that are characteristic of functional and dysfunctional rating scales which includes both question structure and rating scale categories across 17 PROs respectively. Our secondary aim was to develop guidelines for formulating rating scales.
Participants were patients on the cataract surgical waiting list at Flinders Medical Centre, Adelaide, South Australia. All participants were 18 years or older, English speaking, and cognitively able to self-administer PROs. A pack containing 10 PROs rotationally selected from the 17 PROs (Table 1) were mailed to the participants for self-administration. The study was approved by the Flinders Clinical Ethics Committee and adhered to the tenants of the Declaration of Helsinki. All participants provided written informed consent.
A systematic literature search was performed for PROs that were used to measure the impact of cataract and/or outcomes of cataract surgery on a polytomous rating scale (rating scale with more than 2 response categories) in Entrez PubMed. Seventeen PROs met the criteria (Table 1). The 17 PROs (items listed in Additional file 1: Appendix) assess various vision-related quality of life dimensions using ratings of the following four concepts:
Difficulty: e.g. “Do you have difficulty reading small print?” (No difficulty at all = 0, A little difficulty = 1, Moderate difficulty = 2, Very difficult = 3, Unable to do = 4, Don’t do for reasons other than sight/not applicable = 5).
Frequency: e.g. “In the past month, how often have you worried about your eyesight getting worse?” (Not at all = 0, Very rarely = 1, A little of the time = 2, A fair amount of the time = 3, A lot of the time = 4, All the time = 5)
Severity: e.g. “How much pain or discomfort have you had in and around your eyes?” (None = 1, Mild = 2, Moderate = 3, Severe = 4, Very severe = 5).
Global ratings: e.g. “In general would you say your vision (with glasses, if you wear them) is…” (Very good = 1, Good = 2, Fair = 3, Poor = 4).
Rasch analysis is a probabilistic mathematical model that estimates interval-scaled measures from ordinal raw data . Rasch analysis also provides a strong assessment of rating scale functioning. Interested readers are directed to the article by Mallinson for further information on ordinal versus interval data , a chapter by Hays for a non-technical description of Rasch models  and the paper by Linacre on rating scale category analysis .
Assessment of the rating scale
Rating scale functioning can be assessed visually on a category probability curve graph (CPC) which displays the likelihood of each category being selected over the range of measurement of an underlying trait (Figure 1). Each curve in the CPC represents a response category. An important landmark in the CPC is the “threshold”. The threshold is the point at which two neighbouring response categories intersect (Figure 1). At this intersection, a respondent has equal likelihood of choosing one category or the other . The number of thresholds is always one less than the number of response categories, so there are three thresholds for a four-response category. In the well-functioning rating scale shown in Figure 1, thresholds are arranged in a hierarchical order, which is demonstrated by each curve showing a distinct peak, illustrating the position along the continuum (linear scale) where the categories are most likely to be selected [17, 18]. The distance between two neighbouring thresholds defines the size of intervening category. Figure 2a - 2e demonstrate ordered category thresholds, suggesting that the respondents were able to discriminate between these response categories. However, thresholds may not always show ordered arrangement which indicates that the respondents have either not been able to use all categories or had difficulty discriminating between response categories (Figure 2f) [19, 20]. Such rating scales are dysfunctional and require modifications. For this study, we used the following three criteria to evaluate functioning of the rating scales:
Ordered thresholds: This is the fundamental characteristic of a rating scale. Failing to demonstrate ordered thresholds indicates that the choices in the rating scale do not follow the expected hierarchical ordering. Such a rating scale is dysfunctional. Other characteristics (evenness of categories and scale range) are inconsequential when the rating scale has disordered thresholds. Therefore, if the rating has disordered thresholds then the other two criteria were not evaluated.
Evenness of categories: This indicates the relative utilization of response categories by the respondents. It is represented by the standard deviation (SD) of the category widths; the smaller the SD, the more even the categories widths. On the contrary, a dysfunctional rating scale can have categories too close together (indicating overlapping categories) or too far apart from each other (indicating need for more categories).
Scale range: Scale range is the distance between the first and the last category threshold in a rating scale. This indicates the spread of the response categories on the scale range (Figure 1). Larger scale ranges result in greater measurement coverage of the latent trait.
The fit statistics of all the items were also assessed. The fit statistics indicate how well items fit to the Rasch model. There are two types of fit statistics; infit and outfit. Both types of the fit statistics are measured as mean square standardized residuals (MNSQ). The expected statistic is 1.0, with the deviation from this value indicating under- or over-fit. A strict range for acceptable MNSQ is from 0.7 to 1.3, however, a more lenient range of 0.5 and 1.5 is considered productive for the measurement [21, 22]. In this paper, we have considered the lenient range (MNSQ, 05–1.5) as fit to the Rasch model.
This study aims to report the characteristics of rating scale categories in their original format for all items across the 17 different PRO instruments. Interested readers are requested to refer to a series of publications by our group which report how the Rasch analysis was used to optimize the other aspects of measurement properties of these 17 PRO instruments [23–38].
Six hundred and fourteen patients completed at least one PRO instrument. The average response rate for the 17 PRO instruments was 45%. The mean age of the participants was 74·1 years (SD, ± 9.4) and 56% were female. Among the 614 patients, 59% had bilateral cataract, 41% were awaiting second eye surgery and 51% had ocular co-morbidities (glaucoma, 16%; age-related macular degeneration, 9%; and diabetic retinopathy, 4%). The participants had been diagnosed with cataract for an average of 3.2 ± 8.7 years. The mean visual acuity was 0.22 ± 0.20 LogMAR (~6/9.5−1) in the better eyes and 0.55 ± 0.36 LogMAR (~6/24+2) in the worse eyes. Participants had systemic co-morbidities representative of the elderly cataract population in Australia .
Dysfunctional rating scales
Dysfunctional rating scales were found in five of the 17 PROs and were observed for ‘difficulty’ and ‘global vision’ but not for frequency and severity ratings. The PROs with a large number of response categories showed greater numbers of disordered thresholds (Table 2). Disordered thresholds were also evident for PROs with a complicated question layout such as the Activities of Daily Living Scale (ADVS). In the ADVS, items are branched into two-parts (e.g. item 1a: “would you say driving at night with”, item 1b: “is it because of your visual problems that you are unable to drive at night?”). Similarly, the PROs with conceptually similar category labels (e.g. Impact of Visual Impairment [IVI]: “not at all, hardly at all, a little, a fair amount, a lot and can’t do because of eyesight”) and unlabelled categories (e.g. ten-category global rating scale of the National Eye Institute Visual Function Questionnaire, [NEIVFQ]) also demonstrated disordered thresholds.
Functional rating scales
The characteristics of rating scales that demonstrated functional response options are shown in Table 3 (difficulty and frequency) and Table 4 (severity and global vision). Similarly, Figure 2 (a–e) illustrate the performance of difficulty rating scales from five PROs (Visual Symptoms and Quality of life [VSQ]; Cataract Symptom Score [CSS]; Technology of Patient Experience [TyPE]; Visual Function Index [VF14]; and NEIVFQ).
The number of categories with ‘difficulty’ questions ranged from three to five. There were 13 different rating scale formats used in “difficulty” questions, six of which were anchored with “No difficulty” or “Not at all” at one end, and “Unable to do” or “Stopped doing because of eyesight” at the other. In the majority, the first response category represented the most positive option (i.e. “No difficulty”).
Across PROs, there were six different formats of “difficulty” questions with five response categories (Table 3). There was a large variation in the scale range of these categories (2·46 to 7.22 logits). With a simple question format (e.g. item 1: “do you have difficulty recognising people’s faces because of trouble with your eyesight?”) and the five-category option, the VSQ demonstrated a large scale range (6.50 logits), however, response categories showed some unevenness (high SD, 0·91). With a narrower scale range (4.05 logits), the Visual Disability Assessment (VDA) was the best performing PRO with four-response categories in terms of evenness of categories (small SD, 0·28). The VDA follows a simple and uniform question format (e.g. item 4: To what extent, if at all, does your vision interfere with your ability to watch TV?) and categories (“not at all, a little, quite a bit and a lot”) across all the items. For difficulty rating, increasing the number of categories did not always provide a larger coverage of the latent trait and often introduced unevenness of the categories (Table 3).
The number of categories in “frequency” format questions ranged from three to six. The majority of questions were anchored with either “Not at all”, “None of the time”, “Never” or “No” at one end, and “All of the time” or “Always” at the other. In most questionnaires, the most positive category was the first option presented.
The IVI, with six categories, demonstrated the largest scale range (3.68 logits; Table 3). However, the categories demonstrated uneven distribution of categories (high SD, 0·72). Of the three PROs with five-category response formats, the NEIVFQ had the largest scale range (3.58 logits), but also had uneven category distribution (SD, 0.54). Conversely, the CSS with five categories showed evenly distributed categories (SD 0.38), but a smaller scale range (2.93 logits). The Visual Activity Questionnaire (VAQ) with the five-category format was the best performing PRO instrument in terms of scale range (3.55 logits) and evenness of categories (SD, 0.45). The VAQ has items with simple question format (e.g. item 10; “I have trouble reading the menu in a dimly lit restaurant”) and non overlapping categories (“never, rarely, sometimes, often and always”). The VSQ with four response categories demonstrated almost comparable coverage of the trait as the five-category format of the VAQ, but demonstrated highly uneven categories (Table 3). Compared to “difficulty” ratings, items rating “frequency” were limited by either a narrow coverage of the trait or unequal width of the categories which might lead to poor differentiation between respondents.
Unlike for “difficulty” and “frequency”, there was no uniform response format for “severity” questions. The number of categories varied between three and five. While PROs with four or five categories had a large scale range, the unevenness of the categories was a limiting factor. The CSS with the branching question format (e.g. item 1: “Are you bothered by double or distorted vision?” Item 1a: “If so how bothered are you by double or distorted vision?”) showed even categories (small SD, 0·08) but demonstrated the smallest scale range (2.89) (Table 4).
This group represented questions related to global ratings of vision or health. Response categories ranged from three to eight. Questions were formatted with the most positive response option (i.e. “Excellent” and “Perfectly happy”) at one end and the least positive (i.e. “Cannot see at all” and “Poor”) at the other.
The Visual Function and Quality of Life (VF&QOL) questionnaire with a simple question format (“In general, would you say your vision (with glasses, if you wear them”) and four response categories (“very good, good, fair and poor”) had large scale range (6.20 logits) and very even categories (SD, 0.15). The VSQ with eight categories (VSQ V2 and V3) also had large coverage of the trait with even categories (SD, 0.50) (Table 4). The NEIVFQ (six categories) had the largest scale range (10.18 logits) but the categories were uneven (SD, 0.86). The TyPE questionnaire performed poorly in terms of both scale range (3.89 logits) and evenness of categories (SD, 0.95). Thus, global ratings were best served by four categories, as in the VF&QOL questionnaire (scale range = 6.20 and SD, 0.37). Greater response categories (up to seven) may be used in the formats demonstrated herein.
The relationship between misfitting items and rating scales
The majority of the items across the PRO instruments with ordered categories fit the Rasch model (Tables 3 and 4). The PRO instruments that demonstrated disordered rating scale categories had higher representation of misfitting items (Table 2). Overall, the PRO instruments with the better fitted items had the better performing rating scale categories in terms of scale measure range and evenness of category utilization (Tables 3 and 4). Among the items demonstrating ordered categories, the Catquest frequency ratings had maximum number of misfitting items (4 out of 7 items) followed by the VF-14 (3 out of 12 items). Notably, the Catquest had very narrow range (2.78) and the VF-14 demonstrated unevenness of category utilization (SD, 1.38) (Table 3). Furthermore, items with the similar content demonstrated acceptable fit statistics with functional rating scales but not with dysfunctional rating scales. For example, the ADVS item 15bc with the content “driving during the day” misfit the Rasch model, conversely, the VDA item 8 and the NEIVFQ item 15c with the similar content perfectly fit the Rasch model. This observation was consistent across other items having similar contents.
The misfitting items from the PRO instruments with dysfunctional rating scales were removed to assess the effect of the item removal on the category functioning. Table 5 shows the threshold values of the items with disordered categories before and after the removal of the misfitting items. Item removal leads to only small changes in threshold values and does not repair disordering of the categories.
The present study provides a concurrent comparison of the functioning of a wide range of rating scales found in 17 different PROs. Evidence from this study enabled us to formulate an evidence-based guidance for the selection of rating scales for developing new PROs. Although our illustrative examples were drawn from PRO instruments used in ophthalmology, these results may have relevance for other disciplines. However, this should be demonstrated by replication of this work in other disciplines rather than accepting these findings as transferrable.
The results revealed that PROs with a larger number of categories and complicated question formats are more likely to have a dysfunctional rating scale which is also supported by other studies [9, 10, 41, 42]. The Houston Vision Assessment Tool (HVAT) which uses a multiplicative scale (patients make ratings on two scales which are then multiplied to give a more complex final scale) with ten categories demonstrated the highest number of disordered thresholds. The other 10 category scale was also dysfunctional (global ratings of health and vision in the NEIVFQ). However, this may also have been affected by having unlabelled response categories [9, 10, 43]. The format of questions also plays a vital role in producing dysfunctional rating scale. For example, the ADVS has questions presented in a more complicated, branching style which resulted in poor performance (Table 2). Therefore, fewer, concise, and labelled categories just sufficient to maintain adequate measurement precision (i.e. ability to distinguish between the respondents) would ensure good measurement properties whilst maintaining low respondent burden of the PRO [11, 44].
Across the 17 PROs, most of the “difficulty” questions possessed the characteristics (fewer, concise and labelled categories) but not all demonstrated even distribution of categories (Table 3). The VDA demonstrated a superior rating scale performance which is likely due to the design features; an identical four-category format for all questions with conceptually spaces labels, and a simple and uniform question format . While several PROs covered a slightly larger range of the trait, they did so at the sacrifice of equal utilization of categories (i.e. large SD). We found that most of the 5 category scales covered less range than most of the 4 category scales. This illustrates either that more categories can simply add confusion, or that the details of question design and category labelling are also important drivers of rating scale performance than number of categories. The latter conclusion is also supported by the observation of good and bad functioning scales with the same number of response categories (Tables 3 and 4).
Frequency scales did not appear among the dysfunctional sales suggesting people find it easy to respond to frequency ratings. However, “frequency” scales performed less well than ‘difficulty’ scales in terms of both scale range and category evenness (Table 4). An assessment of “severity” scales is difficult given only 4 were included in the study. While two demonstrated excellent range, they suffered from uneven categories. Whereas the one scale with even categories suffered from a limited scale range.
The global rating items were best assessed using a four-category response format, as in the VF&QOL questionnaire, given its high range and even categories. Perhaps the short-description of the categories assisted its good performance. Global ratings with more categories were also functional, the VSQ (seven categories) and the NEIVFQ (five categories) covered a large range and had a fairly even distribution of categories. However, other items in the same instruments, VSQ (eight categories) and NEIVFQ (six categories) had uneven category distribution. Therefore, using more than four or five categories requires careful attention to other attributes of rating scale design. Our findings are also supported by other studies which show that scales with fewer categories out performed the scales with large number of categories [9, 46, 47].
Items with dysfunctional rating scale categories were more likely to misfit the Rasch model (Table 2). Conversely, the PRO instruments with functional rating scales were likely to have very few misfitting items (Tables 3 and 4). We attempted to remove the misfitting items to determine their effect on disordered categories. We observed that this process alone did not repair disordered categories, however, category widths did expand slightly. Notably, items with similar content fit which used with a functional rating scale but not with a dysfunctional rating scale. This suggests that dysfunctional rating scales add noise to items leading to misfit rather than misfitting items damaging the rating scale. However, the actual interaction between item fit statistics and rating scale category functioning is not clear. This requires further investigation. Given disordered rating scale categories can degrade the psychometric properties of a PRO instrument, a sensible post hoc modification by combining categories is a reasonable remedy. Interested readers are requested to refer to a series of publications by our group which report this approach [23–38].
In this study, we observed that the difficulty ratings provided a wider measurement range and evenness of category utilization than frequency ratings (Table 3). This finding reflects properties of the patient data and suggests that people are better at scaling difficulty than they are at scaling frequency. The reasons for this are unclear but may include frequency of problems rating being confounded by frequency of exposure, which may in turn be confounded by limited access due to cost or other variables. However, this does not mean that difficulty ratings must always be preferred over frequency ratings. We advise PRO instrument developers to exercise their judgement while formulating rating categories on the basis of the construct being measured and the research question (e.g. mental health instruments may require frequency ratings because this is part of the definition of the health state).
Similarly, across each of the attributes under measurement, there are rating scales which perform better in terms of metrics such as measurement range or category evenness. However, the rating scale with the widest range is often not the one with the most even categories i.e. the best rating scale is not clear cut. Therefore, while there is value in these results in informing rating scale selection for new instruments, there remain a number of good choices and judgement must be exercised in selection. A potential limitation of this study was that the population of cataract patients who participated in the study had visual disability in the mild to moderate range of measurement of these instruments. This is because the indications for cataract surgery have shifted towards earlier surgery since most of these PROs were developed . This might have influenced utilization of the more negative end response categories, and thereby may have affected the evenness of categories in certain PROs (e.g. VF-14, VFQ, and VSQ). Despite this issue, many of the rating scales were perfectly functional. Another limitation is that is using existing questionnaires in their native formats means that there are numerous factors that vary across questionnaires–number of categories, category labels, question structure and question wording. These factors were uncontrolled, so were not varied systematically to provide definitive evidence about the influence of these factors on the results. Nevertheless, consistent observations across large numbers of rating scales allows for meaningful conclusions to be drawn.
Rating scales are fundamental to data collection, and any loss of measurement quality at this level, will degrade the quality of clinical studies. We found that items with simple and uniform question format, four or five and labelled categories are most likely to be functional and often demonstrate characteristics such as hierarchal ordering, even utilization of categories and a good coverage of the latent trait under measurement. On this basis, we have developed guidelines on the design of rating scales. The guidelines may not translate to all situations, but they may represent useful principles for PRO developers.
Evidence-based guidelines for rating scale design
Use a maximum of five categories for most ratings (e.g. difficulty, frequency, severity) although up to 7 may work for global ratings.
Use short descriptors for categories.
Use non-overlapping categories (e.g. “not at all”, “a little”, “quite a bit” and “a lot”) so that they are mutually exclusive and collectively exhaustive.
Use a simple question format.
Use the same response category format for all questions in a domain (as far as possible).
Too many categories.
Long descriptors for categories.
Using a neutral category.
Conceptually over-lapping categories (for e.g. “hardly at all” and “a little”).
Using a branching question design or other complicated question formats.
Unlabelled categories (for e.g. 0–10 scale).
Proprietary interest statement
The authors have no personal financial interest in the development, production, or sale of any device discussed herein.
Varma R, Richman EA, Ferris FL, Bressler NM: Use of patient-reported outcomes in medical product development: a report from the 2009 NEI/FDA clinical trial endpoints symposium. Investig Ophthalmol Vis Sci 2010, 51: 6095–6103. 10.1167/iovs.10-5627
Fayers PM, Sprangers MA: Understanding self-rated health. Lancet 2002, 359: 187–188. 10.1016/S0140-6736(02)07466-4
Revicki DA, Cella DF: Health status assessment for the twenty-first century: item response theory, item banking and computer adaptive testing. Qual Life Res 1997, 6: 595–600. 10.1023/A:1018420418455
Hobart JC, Cano SJ, Zajicek JP, Thompson AJ: Rating scales as outcome measures for clinical trials in neurology: problems, solutions, and recommendations. Lancet Neurol 2007, 6: 1094–1105. 10.1016/S1474-4422(07)70290-9
Revicki DA: FDA draft guidance and health-outcomes research. Lancet 2007, 369: 540–542. 10.1016/S0140-6736(07)60250-5
Massof RW: Likert and Guttman scaling of visual function rating scale questionnaires. Ophthalmic Epidemiol 2004, 11: 381–399. 10.1080/09286580490888771
Linacre JM: Investigating rating scale category utility. J Outcome Meas 1999, 3: 103–122.
Linacre JM: Optimizing rating scale category effectiveness. J Appl Meas 2002, 3: 85–106.
Garratt AM, Helgeland J, Gulbrandsen P: Five-point scales outperform 10-point scales in a randomized comparison of item scaling for the Patient Experiences Questionnaire. J Clin Epidemiol 2011, 64: 200–207. 10.1016/j.jclinepi.2010.02.016
Preston CC, Colman AM: Optimal number of response categories in rating scales: reliability, validity, discriminating power, and respondent preferences. Acta Psychol (Amst) 2000, 104: 1–15. 10.1016/S0001-6918(99)00050-5
Viswanathan M, Begen M, Dutta S, Childers T: Does a single response category in a scale completely capture a response? Psychol Mark 1996, 13: 457–479. 10.1002/(SICI)1520-6793(199608)13:5<457::AID-MAR2>3.0.CO;2-8
Cox E: The optimal number of response alternatives in a scale: a review. J Market Res Soc 1980, 22: 29–43.
Rasch G: Probabilistic models for some intelligence and attainment tests. Copenhagen: Nielsen and Lydiche; 1960. 2nd edition, Chicago, University of Chicago Press, 1980
Mallinson T: Why measurement matters for measuring patient vision outcomes. Optom Vis Sci 2007, 84: 675–682. 10.1097/OPX.0b013e3181339f44
Hays RD: Item response theory models. In Quality of Life Assessment in Clinical Trials: Methods and Practice. Edited by: Staquet MJ, Hays RD, Fayers PM. New York: Oxford University Press; 1998:183–190.
Tesio L: Measuring behaviours and perceptions: Rasch analysis as a tool for rehabilitation research. J Rehabil Med 2003, 35: 105–115. 10.1080/16501970310010448
Andrich D, de Jong JHAL, Sheridan BE: Diagnostic opportunities with the Rasch model for ordered response categories. In Application of latent trait and latent class models in the social sciences. Edited by: Rost J, Langeheine R. Munster: Waxmann; 1997.
Andrich D: A rating scale formulation for ordered response categories. Psychometrika 1978, 43: 561–573. 10.1007/BF02293814
Wright BD, Mok M: Rasch models overview. J Appl Meas 2000, 1: 83–106.
Reeve BB, Fayers P: Applying item response theory modeling for evaluating questionnaire items and scale properties. 2nd edition. Oxford: Oxford University Press; 2005.
Khadka J, Ryan B, Margrain TH, Court H, Woodhouse JM: Development of the 25-item Cardiff Visual Ability Questionnaire for Children (CVAQC). Br J Ophthalmol 2010, 94: 730–735. 10.1136/bjo.2009.171181
Wright B, Linacre JM: Reasonable mean-square fit values. Rasch Meas Trans 1994, 8: 370.
Gothwal VK, Wright T, Lamoureux EL, Pesudovs K: Psychometric properties of visual functioning index using Rasch analysis. Acta Ophthalmol 2010, 88: 797–803. 10.1111/j.1755-3768.2009.01562.x
Gothwal VK, Wright TA, Lamoureux EL, Khadka J, McAlinden C, Pesudovs K: Improvements in visual ability with first-eye, second-eye, and bilateral cataract surgery measured with the visual symptoms and quality of life questionnaire. J Cataract Refract Surg 2011, 37: 1208–1216. 10.1016/j.jcrs.2011.01.028
Gothwal VK, Wright TA, Lamoureux EL, Lundstrom M, Pesudovs K: Catquest questionnaire: re-validation in an Australian cataract population. Clin Exp Ophthalmol 2009, 37: 785–794. 10.1111/j.1442-9071.2009.02133.x
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Visual Activities Questionnaire: assessment of subscale validity for cataract surgery outcomes. J Cataract Refract Surg 2009, 35: 1961–1969. 10.1016/j.jcrs.2009.05.058
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Cataract symptom score questionnaire: Rasch revalidation. Ophthalmic Epidemiol 2009, 16: 296–303.
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Rasch analysis of visual function and quality of life questionnaires. Optom Vis Sci 2009, 86: 1160–1168. 10.1097/OPX.0b013e3181bab10c
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Cataract Symptom Scale: clarifying measurement. Br J Ophthalmol 2009, 93: 1652–1656. 10.1136/bjo.2009.159806
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Using Rasch analysis to revisit the validity of the Cataract TyPE Spec instrument for measuring cataract surgery outcomes. J Cataract Refract Surg 2009, 35: 1509–1517. 10.1016/j.jcrs.2009.03.056
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Measuring outcomes of cataract surgery using the Visual Function Index-14. J Cataract Refract Surg 2010, 36: 1181–1188. 10.1016/j.jcrs.2010.01.029
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Activities of daily vision scale: what do the subscales measure? Investig Ophthalmol Vis Sci 2010, 51: 694–700. 10.1167/iovs.09-3448
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Multiplicative rating scales do not enable measurement of vision-related quality of life. Clin Exp Optom 2011, 94: 52–62. 10.1111/j.1444-0938.2010.00554.x
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: The impact of cataract surgery questionnaire: re-evaluation using Rasch analysis. Acta Ophthalmol 2011, 89: 423–428. 10.1111/j.1755-3768.2009.01733.x
Pesudovs K, Gothwal VK, Wright T, Lamoureux EL: Remediating serious flaws in the National Eye Institute Visual Function Questionnaire. J Cataract Refract Surg 2010, 36: 718–732. 10.1016/j.jcrs.2009.11.019
Pesudovs K, Wright TA, Gothwal VK: Visual disability assessment: valid measurement of activity limitation and mobility in cataract patients. Br J Ophthalmol 2010, 94: 777–781. 10.1136/bjo.2009.169490
Gothwal VK, Wright TA, Lamoureux EL, Pesudovs K: Rasch analysis of the quality of life and vision function questionnaire. Optom Vis Sci 2009, 86: E836-E844. 10.1097/OPX.0b013e3181ae1ec7
Pesudovs K, Caudle LE, Rees G, Lamoureux EL: Validity of a visual impairment questionnaire in measuring cataract surgery outcomes. J Cataract Refract Surg 2008, 34: 925–933. 10.1016/j.jcrs.2007.12.052
Linacre JM: A User's Guide to Winsteps: Rasch model Computer Programme. Chicago: Mesa Press; 2008.
Kirkwood BJ, Pesudovs K, Latimer P, Coster DJ: The efficacy of a nurse-led preoperative cataract assessment and postoperative care clinic. Med J Aust 2006, 184: 278–281.
Mangione T: Mail surveys: improving the quality. Thousand Oaks: Sage; 1995.
Hjermstad MJ, Fayers PM, Haugen DF, Caraceni A, Hanks GW, Loge JH, Fainsinger R, Aass N, Kaasa S: Studies comparing Numerical Rating Scales, Verbal Rating Scales, and Visual Analogue Scales for assessment of pain intensity in adults: a systematic literature review. J Pain Symptom Manag 2011, 41: 1073–1093. 10.1016/j.jpainsymman.2010.08.016
Svensson E: Concordance between ratings using different scales for the same variable. Stat Med 2000, 19: 3483–3496. 10.1002/1097-0258(20001230)19:24<3483::AID-SIM786>3.0.CO;2-A
Hawthorne G, Mouthaan J, Forbes D, Novaco RW: Response categories and anger measurement: do fewer categories result in poorer measurement? development of the DAR5. Soc Psychiatry Psychiatr Epidemiol 2006, 41: 164–172. 10.1007/s00127-005-0986-y
Pesudovs K, Coster DJ: An instrument for assessment of subjective visual disability in cataract patients. Br J Ophthalmol 1998, 82: 617–624. 10.1136/bjo.82.6.617
Hendriks AA, Vrielink MR, van Es SQ, De Haes HJ, Smets EM: Assessing inpatients’ satisfaction with hospital care: should we prefer evaluation or satisfaction ratings? Patient Educ Couns 2004, 55: 142–146. 10.1016/j.pec.2003.11.006
Hendriks AA, Vrielink MR, Smets EM, van Es SQ, De Haes JC: Improving the assessment of (in)patients’ satisfaction with hospital care. Med Care 2001, 39: 270–283. 10.1097/00005650-200103000-00007
Lundstrom M, Pesudovs K: Catquest-9SF patient outcomes questionnaire: nine-item short-form Rasch-scaled revision of the Catquest questionnaire. J Cataract Refract Surg 2009, 35: 504–513. 10.1016/j.jcrs.2008.11.038
The authors would like to acknowledge the contribution of Mr Thomas Wright who collected and entered the data. This work was supported in part by National Health and Medical Research Council (Canberra, Australia) Centre of Clinical Research Excellence Grant 264620. Konrad Pesudovs and Ecosse Lamoureux are supported by National Health and Medical Research Council (Canberra, Australia) Career Development Awards 426765 and 529902, respectively.
The authors declare that we have no competing interests.
KP led the research program. KP, VG, and JK undertook the data analysis and interpretation. All authors contributed to writing and revising the manuscript and approved the final manuscript.
Authors’ original submitted files for images
Below are the links to the authors’ original submitted files for images.
About this article
Cite this article
Khadka, J., Gothwal, V.K., McAlinden, C. et al. The importance of rating scales in measuring patient-reported outcomes. Health Qual Life Outcomes 10, 80 (2012). https://doi.org/10.1186/1477-7525-10-80
- Patient reported outcomes
- Rating scales
- Response categories
- Quality of life
- Rasch analysis