To determine whether clinical information can practically rule in or rule out the presence of radiographic osteoarthritis in older adults with knee pain.
To determine whether clinical information can practically rule in or rule out the presence of radiographic osteoarthritis in older adults with knee pain.
We conducted a cross-sectional diagnostic study involving 695 adults ages ≥50 years reporting knee pain within the last year identified by postal survey and attending a research clinic. Potential indicators of radiographic osteoarthritis were gathered by self-complete questionnaires, clinical interview, and physical examination. Participants underwent plain radiography (posteroanterior, skyline, and lateral views). Radiographic osteoarthritis was defined as the presence of definite osteophytes in at least 1 joint compartment of the index knee.
Independent predictors of radiographic osteoarthritis were age, sex, body mass index, absence of whole leg pain, traumatic onset, difficulty descending stairs, palpable effusion, fixed-flexion deformity, restricted-flexion range of motion, and crepitus. Using this model, 245 participants had a predicted probability ≥80% (practical rule in), of whom 231 (94%) actually had radiographic osteoarthritis (specificity 93%). Twenty-one participants had a predicted probability <20% (practical rule out), of whom only 2 (10%) had radiographic osteoarthritis (sensitivity 99.6%). The predicted probability of radiographic osteoarthritis for the remaining 429 participants fell into an intermediate category (20–79%).
Simple clinical information can be used to estimate the probability of radiographic osteoarthritis in individual patients. However, for the majority of community-dwelling older adults with knee pain this method enables the presence of radiographic osteoarthritis to be neither confidently ruled in nor ruled out. Prospective validation and updating of these findings in an independent sample is required.
In the UK, an estimated 2 million adults consult their general practitioner with joint symptoms diagnosed as osteoarthritis each year (1). However, attributing joint pain in older adults to osteoarthritis with confidence is difficult (2), and the frequency of osteoarthritis diagnosis varies considerably between general practitioners (3).
Of all the painful conditions presented by older adults to doctors, knee pain is the most common (4). Although osteoarthritis is the most likely diagnosis, general practitioners often request plain radiographs in an attempt to help clinical decision making (5, 6). However, this practice runs contrary to current guidelines (7) that recognize that changes on radiograph are common in the asymptomatic population (8) and, in many cases, do not guide the choice of treatment or alter its outcome.
Relatively simple educational reminders can reduce the number of radiograph requests by general practitioners (9, 10). However, if ascertaining disease status remains a consideration in some consultations, is there an alternative to sending the patient for a radiograph? Can information available at the time of consultation effectively rule in or rule out the presence of radiographic knee osteoarthritis?
In this study, we quantified the simple risk factors and clinical characteristics that can be used, in combination, to estimate the probability of radiographic knee osteoarthritis in older adults with knee pain not associated with specific inflammatory arthropathy. We also investigated the extent to which these simple indicators can effectively rule in and rule out the presence of radiographic knee osteoarthritis. These steps equate to the derivation of a clinical prediction rule before requiring external validation in a separate sample (11).
Participants were recruited from a 2-stage cross-sectional postal survey of all adults ages ≥50 years registered with 3 general practices in North Staffordshire (irrespective of actual consulting patterns). Respondents reporting knee pain within the previous 12 months were invited to attend a research clinic at a local National Health Service Hospital Trust.
The study protocol was approved by North Staffordshire Local Research Ethics Committee (project number 1430) and details have been published elsewhere (12, 13). All participants provided written informed consent to undergo clinical and radiographic assessment. In addition, they were asked for consent to medical record review to assist in excluding preexisting inflammatory disease.
The inclusion criteria for the current analysis were as follows: age ≥50 years, registered with one of the participating general practices at the time of study, responded to both postal questionnaires, consented to further contact, and attended the research clinic. Participants were excluded if they had not experienced knee pain within the 6 months prior to clinic attendance, had a preexisting diagnosis of inflammatory arthropathy in their medical records, or had a total knee replacement in their most affected knee. Thus, the target population for this study were adults with current or recent knee pain of an age range at which knee osteoarthritis would be one of the main diagnoses considered.
All data were planned and gathered prospectively. Participants underwent a standardized clinical interview and physical examination, which were abbreviated versions of assessments developed in an earlier stage of this research (14, 15). Inter- and intrarater reliability have been reported elsewhere (16, 17). Assessments were conducted by 1 of 6 research therapists blinded to the findings from radiography, postal questionnaires, and medical records. Training of the assessors took place prior to the study and was updated after every 100 participants recruited. Training included comparisons against rheumatologists, open and blinded comparisons against each other using “expert patients,” and peer observation. Assessors were issued a manual of detailed protocols for assessing each sign and symptom.
Plain knee radiographs were obtained on the day of clinic attendance in the Trust's radiology department. The films were obtained by a team of 6 radiographers who had all undergone training to standardize the radiographs and met for regular quality control sessions.
Three views were taken of each knee: a weight-bearing semiflexed posteroanterior (PA) view according to the protocol developed by Buckland-Wright et al (18), and lateral and skyline views, both in a supine position with the knee flexed to 45°. Participants filled in a brief self-complete questionnaire about their knee symptoms on the day of their clinic attendance.
The reference standard was definite osteoarthritis from radiographs of the participants' most affected knee (identified by participants at interview). Our definition included osteoarthritis in the tibiofemoral and/or patellofemoral joint. The latter has often been omitted from previous studies but has been shown to be a common form of knee osteoarthritis (19). A single reader (RD), blinded to all other information on participants, scored all films. Films were scored for individual radiographic features, including osteophytes, joint space width, sclerosis, subluxation, and chondrocalcinosis. The atlas and scoring system developed by Altman et al (20, 21) were used for the PA and skyline views and the atlas developed by Burnett et al (22) was used for the lateral view. Additionally, PA and skyline views were assigned a Kellgren and Lawrence (K/L) grade (23). In a subsample of 50 participants, both intra- and interreader reliability for PA K/L score, skyline K/L score, and lateral osteophytes were very good (κ = 0.81–0.98 and 0.49–0.76, respectively). Definite radiographic osteoarthritis was defined as K/L grade 2 or higher for the PA view, K/L grade 2 or higher for the skyline view, the presence of superior or inferior patella osteophytes (lateral view), and/or posterior tibial osteophytes (lateral view) (24). Our definition of radiographic osteoarthritis essentially applied the same principle as earlier studies (i.e., definite osteophyte ) but extended this to all 3 views of the knee.
Prior to analysis, potential indicators were identified from information in the 2 postal questionnaires, the clinical assessment, or the brief self-complete questionnaire. Potential indicators were chosen if they were known risk indicators for radiographic knee osteoarthritis (e.g., age, sex, body mass index [26, 27]), clinical signs and symptoms with a known or putative link to the occurrence of radiographic knee osteoarthritis (e.g., morning stiffness, crepitus, difficulty climbing stairs [28–37]), or clinical manifestations of differential diagnoses (e.g., whole leg pain suggesting widespread pain or referred pain from the lumbar spine, restricted hip range of movement suggesting referred pain from hip osteoarthritis [8, 38–40]). All indicators had to be practicable for assessment within a routine primary care consultation.
We quantified the relationship between each potential indicator and the presence of radiographic knee osteoarthritis by univariable logistic regression. For continuous indicator variables or ordinal variables with several levels, cutoffs were chosen prior to univariable analysis on the basis of previous empirical evidence or, in the absence of this evidence, frequency in the current sample. Variables with a P value less than 0.10 were carried forward to multivariable logistic regression. We used a backward stepwise procedure to fit the regression function to the data (Pr = 0.05; Pe = 0.01). Patients with missing data on any of the univariably associated indicators were excluded from this stage of the analysis. Beta coefficients and odds ratios (ORs) with their respective 95% confidence intervals were used to summarize the marginal contribution of each indicator in the regression function. The resulting multivariable regression function was then fitted to all patients with complete data on indicators included in the multivariable function. The goodness-of-fit of the regression function was assessed by splitting the sample into deciles and plotting the estimated probability against the observed proportion with radiographic osteoarthritis (41).
We used the area under the receiver operating characteristic curve (ROC) as a summary measure of how well the regression function discriminated between patients with and without radiographic knee osteoarthritis. To allow for overoptimism in the regression function, we performed bootstrapping techniques as a form of internal validation (42). The resulting multivariable function was applied to 200 bootstrap samples, with replacement, to determine the level of bias in each of the observed beta coefficients.
Using the bias-corrected regression function, we described the proportion of the sample falling into the practical rule-in category (≥80% probability of radiographic osteoarthritis) and practical rule-out category (<20% probability). Finally, using the bias-corrected beta coefficients, we derived a simple scoring method (43) that would enable the probability of radiographic osteoarthritis to be calculated for an individual patient with knee pain. All analysis was carried out in Stata 7.0 (StataCorp, College Station, TX).
Between August 2002 and September 2003, a total of 819 individuals ages ≥50 years who had knee pain in the past 12 months attended the research clinics. Compared with all 3,106 survey respondents reporting knee pain in the previous 12 months, those attending the research clinics tended to be younger, male, married, have more education, and be less likely to come from routine occupational backgrounds or to be anxious or depressed (Table 1). The number of patients who were eligible and had complete data from the 819 clinic attendees is shown in Figure 1.
|Characteristic||Reported knee pain in last 12 months (n = 3,106)||Attended research clinic (n = 819)|
|A||1,227 (40)||302 (37)|
|B||1,251 (40)||330 (40)|
|C||628 (20)||187 (23)|
|50–59||898 (29)||236 (29)|
|60–69||964 (31)||312 (38)|
|70–79||822 (26)||222 (27)|
|≥80||422 (14)||49 (6)|
|Female sex||1,832 (59)||440 (54)|
|Married/cohabiting||1,985 (65)||599 (74)|
|Higher education||327 (11)||117 (15)|
|Currently employed||668 (22)||167 (21)|
|Occupational class: manual||1,904 (68)||420 (54)|
|Baseline SF-12 score, mean ± SD|
|Physical (0–100)||37.0 ± 12.2||37.6 ± 11.9|
|Mental (0–100)||47.9 ± 11.6||50.6 ± 10.9|
|Baseline HAD anxiety|
|None (0–7)||1,656 (55)||500 (62)|
|Possible (8–11)||842 (28)||217 (27)|
|Probable (12–21)||508 (17)||85 (11)|
|Baseline HAD depression|
|None (0–7)||2,198 (73)||663 (83)|
|Possible (8–11)||593 (20)||102 (13)|
|Probable (12–21)||221 (7)||37 (4)|
|Baseline WOMAC score, mean ± SD|
|Pain (0–20)||–||6.4 ± 4.4|
|Stiffness (0–8)||–||2.7 ± 1.9|
|Physical function (0–68)||–||20.9 ± 15.2|
Of the 650 eligible participants with complete data on all indicators, 452 (70%) had radiographic knee osteoarthritis. A total of 257 patients were classified as having moderate or severe radiographic osteoarthritis (K/L grade 3 or 4 in either the tibiofemoral or patellofemoral joint, or grade 3 posterior or lateral osteophytes).
Of the 57 candidate indicators, 17 were not associated with the presence of definite radiographic knee osteoarthritis in univariable analysis. A further 11 indicators were excluded from the multivariable stage due to high collinearity (see Appendix A, available at the Arthritis Care & Research Web site at http://www.interscience.wiley.com/jpages/0004-3591:1/suppmat/index.html).
Of the remaining 29 indicators with a univariable P value less than 0.10, 10 were independently associated with the presence of radiographic knee osteoarthritis in the multivariable logistic regression function. This model was then refitted to all 695 participants with complete data for these 10 indicators. Older age (adjusted OR 2.0 for ages 60–69 years and 2.8 for ages ≥70 years), male sex (OR 2.1), overweight (OR 2.2) or obese (OR 3.3), history of the knee problem starting following an accident or injury in the past (OR 1.8), difficulty descending stairs due to the knee problem (OR 1.3 for mild, 2.8 for moderate, and 3.0 for severe/extreme), presence of palpable effusion on examination (OR 2.2 for mild and 1.8 for moderate/gross), fixed-flexion deformity (OR 7.1), restricted knee flexion range of motion (OR 2.3), and the presence of palpable coarse crepitus (OR 1.4 for possible and 2.4 for definite) all increased the likelihood of radiographic knee osteoarthritis being present. Pain in the whole leg was associated with a lower likelihood of radiographic knee osteoarthritis (OR 0.4) (Tables 2 and 3).
|Indicator||Total, no.||ROA, no.||Uncorrected function|
|β||(95% CI)||OR||(95% CI)||P|
|60–69||278||203||0.71||(0.28, 1.14)||2.0||(1.3, 3.1)||0.001|
|≥70||210||170||1.05||(0.54, 1.55)||2.8||(1.7, 4.7)||< 0.001|
|Male||314||245||0.74||(0.35, 1.13)||2.1||(1.4, 3.1)||< 0.001|
|Body mass index, kg/m2|
|25–29.9||304||210||0.77||(0.24, 1.30)||2.2||(1.3, 3.7)||0.004|
|≥30||281||217||1.19||(0.63, 1.75)||3.3||(1.9, 5.7)||< 0.001|
|Started after accident/injury|
|Yes||102||81||0.60||(0.03, 1.18)||1.8||(1.0, 3.3)||0.04|
|Pain in whole leg|
|Yes||85||47||−0.99||(−1.56, −0.43)||0.4||(0.2, 0.6)||0.001|
|Difficulty descending stairs|
|Mild||216||138||0.29||(−0.17, 0.76)||1.3||(0.8, 2.1)||0.21|
|Moderate||189||152||1.04||(0.50, 1.57)||2.8||(1.7, 4.8)||< 0.001|
|Severe/extreme||111||93||1.11||(0.41, 1.81)||3.0||(1.5, 6.1)||0.002|
|Mild||84||73||0.81||(0.06, 1.56)||2.2||(1.1, 4.7)||0.04|
|Moderate/gross||168||134||0.56||(0.09, 1.53)||1.8||(1.1, 2.8)||0.02|
|Yes||85||82||1.96||(0.74, 3.18)||7.1||(2.1, 24.1)||0.002|
|Knee flexion ROM, degrees|
|<120||96||85||0.83||(0.07, 1.60)||2.3||(1.1, 4.9)||0.03|
|Possible||130||98||0.34||(−0.17, 0.85)||1.4||(0.8, 2.3)||0.20|
|Definite||153||130||0.89||(0.34, 1.44)||2.4||(1.4, 4.2)||0.001|
|Constant||−5.04||(−6.89, −3.18)||< 0.001|
|Indicator||Total, no.||ROA, no.||Bias-corrected function (after bootstrapping)|
|β||(95% CI)||OR||(95% CI)|
|60–69||278||203||0.69||(0.26, 1.19)||2.0||(1.3, 3.3)|
|≥70||210||170||1.00||(0.63, 1.53)||2.7||(1.9, 4.6)|
|Male||314||245||0.74||(0.30, 1.15)||2.1||(1.4, 3.2)|
|Body mass index, kg/m2|
|25–29.9||304||210||0.73||(0.11, 1.21)||2.1||(1.1, 3.3)|
|≥30||281||217||1.14||(0.56, 1.64)||3.1||(1.7, 5.2)|
|Started after accident/injury|
|Yes||102||81||0.61||(0.03, 1.27)||1.8||(1.0, 3.5)|
|Pain in whole leg|
|Yes||85||47||−0.98||(−1.65, −0.55)||0.4||(0.2, 0.6)|
|Difficulty descending stairs|
|Mild||216||138||0.29||(−0.12, 0.80)||1.3||(0.9, 2.2)|
|Moderate||189||152||1.02||(0.50, 1.66)||2.8||(1.7, 5.3)|
|Severe/extreme||111||93||1.10||(0.38, 1.94)||3.0||(1.5, 7.0)|
|Mild||84||73||0.72||(−0.22, 1.70)||2.1||(1.0, 5.5)|
|Moderate/gross||168||134||0.52||(0.11, 1.10)||1.7||(1.1, 3.0)|
|Yes||85||82||1.87||(1.04, 3.19)||6.5||(2.8, 24.4)|
|Knee flexion ROM, degrees|
|<120||96||85||0.76||(0.07, 1.52)||2.1||(1.1, 4.6)|
|Possible||130||98||0.32||(−0.09, 0.95)||1.4||(0.9, 2.5)|
|Definite||153||130||0.84||(0.27, 1.42)||2.3||(1.3, 4.1)|
The formula of the multiple logistic regression function was used to estimate the probability of radiographic knee osteoarthritis for each individual based on their clinical profile. The individual probabilities ranged from 0.07 to 0.99 (where 0 represents certainly absent and 1 represents certainly present). The function was a good fit for the data (Pearson's χ2 = 430.89, P = 0.88) (calibration plot not shown). The area under the ROC curve was 0.80, suggesting reasonable discrimination between patients with and those without radiographic knee osteoarthritis (41). Bootstrapping revealed only a very minor degree of overfitting in the model, with the degree of shrinkage of coefficients for each indicator in the model well below the level indicative of serious bias (25% of the standard error of the coefficient ) (data not shown).
The effect of applying the bias-corrected function to individuals in the sample is summarized in Table 4. A total of 245 individuals fell into the practical rule-in category. Of these, 231 (94%) did have radiographic knee osteoarthritis on radiograph. Twenty-one individuals fell into the practical rule-out category, of whom only 2 (10%) had radiographic knee osteoarthritis. The remaining 429 individuals fell into an indeterminate category (estimated probability 20–79%). Of these, 249 (58%) had radiographic knee osteoarthritis. Adopting a threshold of predicted probability of ≥50% identified 266 (96%) of 277 individuals with moderate or severe radiographic knee osteoarthritis.
|Estimated probability of definite ROA, %‡||Severity of ROA†|
|90–100||110 (40)||26 (13)||2 (4)||2 (1)||140 (20)|
|80–89||64 (23)||31 (15)||1 (2)||9 (6)||105 (15)|
|70–79||43 (16)||34 (17)||12 (21)||17 (11)||106 (15)|
|60–69||28 (10)||33 (16)||12 (21)||27 (17)||100 (14)|
|50–59||21 (8)||26 (13)||6 (11)||19 (12)||72 (10)|
|40–49||5 (2)||24 (12)||6 (11)||16 (10)||51 (7)|
|30–39||4 (1)||22 (11)||8 (14)||24 (15)||58 (8)|
|20–29||2 (1)||7 (3)||6 (11)||27 (17)||42 (6)|
|10–19||0 (0)||2 (1)||3 (5)||15 (10)||20 (3)|
|0–9||0 (0)||0 (0)||1 (2)||0 (0)||1 (<1)|
|Any||277 (100)||205 (100)||57 (100)||156 (100)||695 (100)|
Points were assigned to each indicator by dividing the bias-corrected coefficient by the value of the smallest coefficient and rounding to the nearest 0.5 points (see Appendix B, available at the Arthritis Care & Research Web site at http://www.interscience.wiley.com/jpages/0004-3591:1/suppmat/index.html). Adding the relevant points for an individual patient provides a total score that is then converted into an estimated probability of radiographic knee osteoarthritis. For example, a 67-year-old (2.0 points) overweight (2.5 points) man (2.5 points) who reports localized knee pain (3.5 points) that first began after a previous knee injury (2.0 points), who now reports moderate difficulty going downstairs due to the knee (3.5 points), and who on examination has a mild effusion (2.5 points) and definite crepitus (3.0 points) but no fixed-flexion deformity or limited knee flexion would have a total score of 21.5. The estimated probability of that individual having radiographic knee osteoarthritis is >90%.
Our purpose was to establish whether information potentially available at the time of a primary care consultation could be used to effectively rule in or rule out the presence of radiographic osteoarthritis in older adults presenting with knee pain. Our findings demonstrate that this can be done with partial success.
Estimating the probability of radiographic knee osteoarthritis among symptomatic individuals requires a combination of several pieces of information: no single indicator adequately discriminates between patients with and those without structural disease. Diagnosis in clinical practice rarely relies on a single test, and diagnostic research therefore relies on multivariable modeling (48–50). Well-recognized risk indicators (e.g., age, body mass index) increase the probability that the patient has radiographic knee osteoarthritis, as does information from the history (e.g., difficulty descending stairs) and physical examination (e.g., restricted movement at the knee, coarse crepitus).
But despite a relatively well-calibrated multivariable model, when we used this model to estimate the probability of radiographic knee osteoarthritis for individual patients, only a minority of our sample fell into a practical rule-in category (≥80% probability) and very few fell into a practical rule-out category (<20% probability). In short, a fairly comprehensive assessment of risk indicators and clinical signs and symptoms still leaves us unable to confidently rule in or rule out radiographic knee osteoarthritis in 3 out of 5 older adults experiencing knee pain in the community. We do not advocate ordering radiographs to resolve this uncertainty. Instead, given the difficulty in discriminating patients with radiographic osteoarthritis from those without, and given that structural change on radiograph may be a relatively late indicator of disease, the responsibility is perhaps more on justifying why knee pain in this age group (after excluding relatively rare specific differential diagnoses) should not be managed as if it were osteoarthritis.
Many previous studies have described the association between risk factors, clinical variables, and radiographic knee osteoarthritis, but often only in univariable analyses. There are few comparable studies in which multivariable analysis has been conducted with the express purpose of individual risk prediction. LaValley et al found that brief questionnaire-based screening instruments failed to adequately discriminate between patients with and those without symptomatic radiographic knee osteoarthritis (symptoms on most days and radiographic evidence of knee osteoarthritis) in the general population (33). Our focus was rather different. We have argued that, from a clinical perspective, the starting point is undifferentiated knee pain. Ascertaining symptom status poses little challenge: we ask the patient. Identifying the presence of radiographic knee osteoarthritis in those with knee pain is the challenging part. Like us, Claessens et al concluded that “no single clinical finding can accurately predict radiographic OA” in symptomatic individuals (29). The content and performance of their multivariable model were not fully reported. In contrast, we found that clinical variables do add to the prediction of radiographic knee osteoarthritis, as they have done in similar studies for hip osteoarthritis (40, 51). Variables used in the American College of Rheumatology clinical classification criteria for knee osteoarthritis (duration of morning stiffness, bony enlargement, and crepitus) (28) were associated with radiographic knee osteoarthritis in the current study, but only crepitus was retained in the multivariable model.
We defined our target population as adults ages 50 years and older (an age at which osteoarthritis becomes a common diagnosis in primary care) with current or recent knee pain who did not have a preexisting medical diagnosis of specific inflammatory arthropathy. This definition may be criticized for being too broad. It has been argued that “using less frequent knee pain together with radiographic osteoarthritis … corresponds to an entity which is less consistently reflective of osteoarthritis” (33). We would argue that osteoarthritis symptoms can be less frequent and such individuals do present to general practice in significant numbers where their symptoms may be attributed to osteoarthritis (52). A similar argument concerns the inclusion of individuals who reported knee pain as part of a more diffuse pain problem. Pain persistence (pain days in last 6 months), widespread pain, and whole leg pain were included in our list of candidate indicators.
Our reference standard included tibiofemoral and patellofemoral radiographic osteoarthritis. Risk factors may differ between the two (53). However, the combined pattern of osteoarthritis was the most common in our sample, and has had the strongest associations with risk indicators in several previous studies (54–56). Rather than looking separately at tibiofemoral and patellofemoral radiographic osteoarthritis, we thought that discriminating between any or no radiographic osteoarthritis was an appropriate choice and probably better reflects current clinical distinctions. Distinguishing between mild and severe radiographic osteoarthritis might also be important. Using our regression function, the estimated probability of patients with moderate or severe radiographic disease was significantly higher than those with milder forms of disease. For example, only 11 of 172 individuals with an estimated probability <50% had moderate or severe radiographic osteoarthritis. It may be that selecting a more severe threshold of radiographic disease would permit greater discrimination.
We considered many candidate indicators of radiographic knee osteoarthritis, each justified on the basis of prior evidence or clinical knowledge. Occupation and sports participation have been highlighted as risk indicators for knee osteoarthritis (27) but information about these was not gathered in the current study. Participating practices were located partly within areas of traditional mining and farming communities, which might explain the higher prevalence of radiographic knee osteoarthritis among men in our sample. The inclusion of these additional indicators may modify our model but would also increase its complexity with potentially only a small incremental benefit to discrimination (11, 57). Ninety-five participants had 1 or more missing values on either the outcome or diagnostic indicators. These individuals were more likely to be women, older, and have milder symptoms. Nevertheless, when 45 of these individuals were reintroduced for the final multivariable model, there was little noticeable change in the regression coefficients and age, sex, and a marker of clinical severity (difficulty descending stairs) were included in the multivariable regression function. We therefore do not believe that missing data pose a significant threat of bias in our results.
Our model was derived within a single sample of participants drawn from one geographic area. Bootstrap procedures were used to guard against overfitting our logistic regression function. However, prospective validation and updating in a separate sample, particularly one more ethnically diverse than the present sample (individuals from ethnic minorities constituted <1% of the current sample), would be beneficial.
The majority of older persons with knee pain have some evidence of radiographic osteoarthritis in their most affected knee. The prior probability of radiographic osteoarthritis among symptomatic older adults is high. Simple clinical information can help estimate the probability of radiographic osteoarthritis in individual patients, although in many cases this will not allow radiographic osteoarthritis to be ruled in or ruled out with a high degree of confidence.
Dr. Peat had full access to all of the data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis.
Study design. Peat, Thomas, Duncan, Wood, Wilkie, Hill, Hay, Croft.
Acquisition of data. Peat, Thomas, Duncan, Wood, Wilkie, Hill.
Analysis and interpretation of data. Peat, Thomas, Duncan, Wilkie, Hay, Croft.
Manuscript preparation. Peat, Thomas, Duncan, Wood, Wilkie, Hill, Hay, Croft.
Statistical analysis. Thomas.
The authors thank the administrative and health informatics staff at Keele University's Primary Care Sciences Research Centre, and staff of the participating general practices and Haywood Hospital. We also gratefully acknowledge the assistance of Professor C. Buckland-Wright for advice and training for the radiograph protocols. Dr. K. Dziedzic, Ms H. Myers, Ms J. Handy, and Ms C. Clements contributed to aspects of the design of the Knee Clinical Assessment Study (CAS[K]) and the collection of clinical data. Drs. G. Carpenter, L. Coar, V. Cooper, P. Dawes, J. Greig, A. Hassell, M. Porcheret, M. Shadforth, and A. Rees contributed to aspects of the conception and design of CAS(K). Dr. J. Saklatvala, Ms C. Jackson, Ms J. Myatt, Ms J. Wisher, Ms S. Stoker, Ms S. Yates, and Ms K. Hickson from the Department of Radiography, Haywood Hospital conducted all study radiographs.