- Open Access
Illustrating risk difference and number needed to treat from a randomized controlled trial of spinal manipulation for cervicogenic headache
© Haas et al; licensee BioMed Central Ltd. 2010
- Received: 5 March 2010
- Accepted: 24 May 2010
- Published: 24 May 2010
The number needed to treat (NNT) for one participant to benefit is considered a useful, clinically meaningful way of reporting binary outcomes from randomized trials. Analysis of continuous data from our randomized controlled trial has previously demonstrated a significant and clinically important difference favoring spinal manipulation over a light massage control.
Eighty participants were randomized to receive spinal manipulation or a light massage control (n = 40/group). Improvements in cervicogenic headache pain (primary outcome), disability, and number in prior four weeks were dichotomized into binary outcomes at two thresholds: 30% representing minimal clinically important change and 50% representing clinical success. Groups were compared at 12 and 24-week follow-up using binomial regression (generalized linear models) to compute the adjusted risk difference (RD) between groups and number needed to treat (NNT) after adjusting for baseline differences between groups. Results were compared to logistic regression results.
For headache pain, clinically important improvement (30% or 50%) was more likely for spinal manipulation: adjusted RD = 17% to 27% and NNT = 3.8 to 5.8 (p = .005 to .028). Some statistically significant results favoring manipulation were found for headache disability and number.
Spinal manipulation demonstrated a benefit in terms of a clinically important improvement of cervicogenic headache pain. The use of adjusted NNT is recommended; however, adjusted RD may be easier to interpret than NNT. The study demonstrated how results may depend on the threshold for dichotomizing variables into binary outcomes.
ClinicalTrials.gov NLM identifier NCT00246350.
- Risk Difference
- Percent Improvement
- Spinal Manipulation
- Headache Pain
- Light Massage
The number needed to treat (NNT) for one participant to benefit from an intervention is considered a useful, clinically meaningful way of reporting binary outcomes from randomized trials [1, 2]. It is the number of participants that must be treated for one clinical event to be attributable to a treatment above and beyond the benefit from a control. NNT is computed as one divided by risk difference (RD), where the RD (also known as absolute risk or absolute risk reduction), is the difference in proportions of participants achieving a clinical benefit in the treatment and control groups. For example, there is a RD of 20% when 60% of the participants in the treatment group achieve a clinical success as compared to 40% of participant s in the control group. In this case, the NNT would be 5.0.
Reporting NNT and RD has been recommended for randomized trials in the CONSORT statement , but these statistics have not been well utilized . These measures can reveal important effects of care that are not reflected in the odds ratio, a statistic often reported for binary data [5, 7].
Clearly, binary analysis is appropriate with naturally dichotomous variables, such as cure or death. When outcomes are evaluated as continuous variables, such as scales that measure pain intensity and functional disability, meaningful scale cut points must be identified to define the clinical result of interest. One reasonable cut point is the minimal clinically important difference or change to the participant. Ostello et al  reported the results of a literature review and expert panel. They concluded that a 30% improvement was a robust delineator of minimal important change across a number of pain and functional disability instruments. Thirty percent improvement was used in the UK BEAM trial for computing NNT . Fritz et al  recommend using clinical success as an outcome, which they defined as 50% improvement in function disability for low back pain participants. The 50% improvement threshold is commonly reported in headache studies and we have previously reported this measure for headache pain and frequency .
We conducted a randomized trial evaluating the efficacy of spinal manipulation and comparing two doses of intervention provided by a chiropractor for the care of cervicogenic headache [11, 13]. Spinal manipulation had a clinically important advantage over light massage in headache pain, number, and disability; there was little effect of dose. A path analysis suggested that a trial on manipulation can be designed where expectancy and the participant-provider encounter have minimal effect on outcomes . Also, cervical pain-pressure thresholds may be determinants of clinical outcomes . Our primary publication emphasized the differences between groups evaluated on continuous data scales, but did not give perspective on the proportion of participants expected to benefit from spinal manipulation .
The purpose of this article is to report clinician-friendly outcomes, RD and NNT for a minimal clinically important change (≥30% improvement) and successful treatment (≥ 50% improvement), and to discuss some advantages and shortcomings of these summary measures. Also useful in practice for formulating prognosis are charts estimating the probability of achieving different levels of improvement following treatment. For researchers, statistical methods are recommended for adjusting RD and NNT for baseline differences between treatment and control groups.
The methods for this prospective randomized controlled trial are presented in detail in two previous publications [11, 12]. Briefly, participants were randomized to receive either spinal manipulation or a minimal light massage control (n = 40 per group) provided by a chiropractor. Participants were further randomized to eight or 16 treatments over eight weeks. Treatment visits were 10 minutes in duration. Dose had little effect on outcomes in this study , and was therefore ignored in the analysis for this report. Randomization was conducted using computer-generated, design adaptive allocation to balance seven variables across groups (see Statistical analysis). Allocation was concealed from all personnel prior to randomization using this technique [11, 12].
Data used in this report were collected at two baseline screening visits and by mailed questionnaire at 12 and 24 weeks. Missing data were imputed from outcomes collected through phone interview by a blinded research assistant at four, eight, 16, and 20 weeks. The primary outcome, identified in advance, was self-reported cervicogenic headache pain intensity. Analysis was conducted using the intention-to-treat principle. The trial was approved by the University of Western States Institutional Review Board (FWA 851).
Volunteers were eligible if they had a history of at least 5 cervicogenic headaches per month for 3 months, with cervicogenic headache as defined by the International Headache Society in 1998 (excluding the radiographic criterion) . Participants had a minimum score of 25 on the 100-point pain intensity scale to prevent floor effects. Participants were ineligible if they had contraindications to spinal manipulation , referred neck pain of organic origin, or pregnancy. Persons were also ineligible if they experienced other types of headache with etiologies that might have confounded the effects of manipulation on the cervicogenic component: cluster, metabolic/toxic, sinus, and headache associated with temporomandibular disease, tumors, and glaucoma [11, 12].
Assessment and intervention
A chiropractor/faculty member with 15 years experience screened volunteers for study eligibility through case history, standard orthopedic/neurological exam, heat sensitivity test, and 3-view cervical x-ray using the protocols of Vernon  and Souza  for cervicogenic headache and those of Gatterman and Panzer  for the cervical region. Four chiropractors with over 20 years of experience each served as the study treatment providers.
The treatment group received high velocity, low amplitude spinal manipulation of the cervical and upper thoracic (transitional region) spine at each visit as described by Peterson and Bergmann . Modifications in manipulation recommended for older participants were permitted as required [19, 20]. To relax the neck and upper back in preparation for spinal manipulation , the chiropractor administered a moist heat pack for five minutes and conducted a light massage for two minutes (described next).
The control group received five minutes of moist heat followed by five minutes of light massage. Light massage consisted of gentle effleurage (gliding) and gentle pétrissage (kneading) of the neck and shoulder muscles [22, 23]. This allowed us to control contact with the participant with an intervention that was expected to have relatively small specific effects. This was because SMT had been shown to be superior to deep massage and the LM application was much lighter and of much shorter duration than found in massage trials and common practice [25, 26].
Study variables for this report
Cervicogenic headache pain (CGH) intensity and disability were evaluated using the Modified Von Korff pain scale of Underwood et al . The primary outcome was the pain scale and is the average of three 11-point numerical rating scales: CGH pain today, worst CGH pain in the last four weeks, and average CGH pain in the last four weeks. The disability scale (secondary outcome) is the average of three 11-point scales evaluating interference with daily activities, social and recreational activities, and the ability to work outside or around the house. The scales are scored from 0 to 100 with a lower score more favorable. The third outcome was the number of CGH in the previous four weeks. Baseline variables were used as covariates in the analysis. These included CGH pain and number, age, gender, self-reported previous diagnosis of migraine, confidence in care, and expected number of treatments needed for improvement. Treatment expectancy was evaluated with six-point Likert scales on participant confidence in the success of the two interventions using Interstudy's Low Back Pain TyPE Specification instrument .
An intention-to-treat analysis was conducted with each participant included in the original allocation group with missing data imputed . Five subjects were eliminated from this analysis due to lack of follow-up after baseline. For this secondary analysis, the continuous outcomes were dichotomized with 30% and 50% improvement as the threshold values for benefit and success, respectively.
Adjusted RDs between manipulation and control interventions were calculated using a test of proportions called binomial regression (a generalized linear regression model) that takes into account differences between groups in baseline covariates [29, 30]. The covariates for all analyses are listed under Study variables above. Multiple logistic regression was first performed to calculate an initial estimate of the mean of the dependent variable for the binomial regression analysis. When a binomial regression model failed to converge and yield an estimate of the RD, multiple linear regression was used to estimate the RD between groups [31, 32]. All analyses used robust standard errors to minimize distributional assumptions . The adjusted NNT and 95% confidence intervals were then computed by inverting the adjusted RD and its 95% confidence limits. Logistic regression was also used to compute odds ratios comparing interventions adjusted for the baseline covariates . All analyses were conducted with Stata 11 (Stata Corp, College Station, TX).
Baseline participant characteristics*
(n = 40)
(n = 40)
(n = 80)
37 ± 11
36 ± 11
36 ± 11
Pain intensity (100-point scale)
50.9 ± 17.0
57.8 ± 16.3
54.3 ± 16.9
Number of headaches in the past 4 weeks
15.4 ± 8.0
16.0 ± 7.8
15.7 ± 7.9
Disability (100-point scale)
42.7 ± 23.1
47.4 ± 22.9
45.0 ± 22.9
Migraine sufferer (self report)
Optimal number of treatments (4 - 20)
12.9 ± 4.9
12.5 ± 5.1
12.7 ± 5.0
14.3 ± 4.8
14.2 ± 5.4
14.3 ± 5.0
Confidence in success of SMT
4.2 ± 1.2
4.1 ± 1.3
4.1 ± 1.3
Confidence in success of LM
4.0 ± 1.2
4.1 ± 1.2
4.1 ± 1.2
Cervicogenic headache pain
Participants obtaining 30% and 50% improvement in outcomes: risk difference (RD) and number needed to treat (NNT)*
(n = 36)
(n = 39)
(95% CI worst to best)
Cervicogenic headache pain scale †
20% (2, 37)
5.1 (40, 2.7)
17% (2, 33)
5.8 (54, 3.1)
26% (8, 45)
3.8 (13, 2.2)
27% (8, 46)
3.8 (13, 2.2)
Cervicogenic headache number (in last 4 wk)
23% (6, 40)
4.3 (16, 2.5)
14% (1, 27)
7.2 (152, 3.7)
21% (0, 43)
4.7 (442, 2.4)
14% (-2, 30)
7.2 (-42, ± ∞, 3.3)
Cervicogenic headache disability scale †
15% (-9, 39) ‡
6.7 (-3.5, ± ∞, 2.6)
-7% (-29, 15)
-15 (-11, ± ∞, 6.5)
29% (6, 52) ‡
3.5 (17, 1.9)
20% (-1, 42)
4.9 (-105, ± ∞, 2.4)
Table 2 can be interpreted as follows, using the third row of data as an example (participants achieving 50% improvement at 12 weeks): Successful outcomes were achieved in 42% of SMT participants and 23% of control participants. When correcting for baseline differences between the two study groups, the adjusted RD = 26%. This means that we can estimate that 26% or about one in four participants are expected to have a successful treatment outcome that is directly attributable to SMT above the success rate that we can expect from a minimal light massage. The confidence interval for the adjusted RD was 7.9% to 45%. This tells us that the true RD for the study population may be considerably lower or higher than 26%; this is a consequence of the modest sample size. The statistical significance is P = .005. It suggests that the favorable results for SMT are unlikely due to chance (sampling error) alone. The p-value applies to both the adjusted RD and NNT. Putting it all together, we can conclude that an advantage for SMT is likely real (P = .005) and substantial (adjusted RD = 26%), but the advantage can range with equal probability from the small (lower 95% confidence limit = 7.9%) to the extremely large (upper 95% confidence limit = 45%).
The adjusted NNT is, in essence, a rewording of the adjusted RD. It shows that we expect to treat 3.8 participants for one participant to benefit from SMT over the control intervention (i.e., about one in four participants benefit directly). The confidence interval shows that the NNT in the true study population is likely between a mediocre 13 and an extremely favorable two. Note that in general, NNT of large magnitude indicate trivial differences between interventions and small NNT indicate large differences. One is the smallest possible NNT and occurs in the extremely unlikely case of a 100% success in the treatment group and 0% success in the control group.
Cervicogenic headache number
Reduction in the monthly number of headaches also favored SMT (Table 2). At 12 weeks, the adjusted RD was 21% to 23% and the adjusted NNT was 4.3 to 4.7 participants. At 24 weeks, the adjusted RD was 14% and the adjusted NNT was 7.2. The results were statistically significant (P < .05) except for 50% improvement at the 24-week follow-up (P = .094).
Note that for results that are not statistically significant, one side of the 95% confidence interval (CI) will be negative for both RD and NNT. The CI can be interpreted moving from the left limit to the right limit of the CIs for 50% improvement at 24 weeks in Table 2. For RD, the CI is -2 to 30. The left limit is -2, indicating a possible advantage for the control group; the CI passes zero (the break-even point); and the upper limit is 30, indicating the largest advantage for the treatment group in the CI. The CI for NNT (-42, ± ∞, 3.3) is more complicated. It starts with the smallest negative number on the left (-42), which indicates the largest advantage for the control group. Moving toward the center of the CI, the negative value increases to negative infinity (NNT = 1/RD = -1/0 = -∞), the smallest advantage for the control (none). As the break-even point is crossed, the value flips to positive infinity (+1/0 = +∞), the smallest advantage for SMT (none). The positive number decreases in size until the upper limit is reached (3.3), the largest advantage for the treatment group.
Cervicogenic headache disability
Results were mixed for headache disability (Table 2). Outcomes were favorable for manipulation at 50% improvement albeit marginally failing to reach statistical significant at 24 weeks (NNT = 3.5, P = .015 and NNT = 4.9, P = .061). There were no significant outcomes for 30% improvement.
Risk differences and odds ratios
Participants obtaining 30% and 50% improvement in outcomes: odds ratio*
SMT (n = 36)
LM (n = 39)
adjusted odds ratio
Cervicogenic headache pain scale †
2.2 (0.8, 6.0)
2.3 (0.8, 6.5)
3.0 (1.1, 8.3)
3.6 (1.3, 9.7)
Cervicogenic headache number (in last 4 wk)
4.4 (1.3, 14.3)
3.1 (0.9, 11.2)
2.6 (0.9, 7.5)
1.9 (0.7, 5.2)
Cervicogenic headache disability scale †
2.0 (0.7, 5.7)
0.9 (0.3, 2.4)
3.8 (1.3, 11.0)
2.2 (0.9, 5.9)
Expected improvement in practice
The analysis of percent improvement shows a benefit of spinal manipulation compared to a minimal light massage control at 12 and 24 weeks for the relief of cervicogenic headache pain. The evidence is not as consistent for the other outcomes, but some positive results were observed for headache number particularly in the short term.
The evidence-based practice movement favors the use of the NNT ; this requires dichotomizing continuous outcomes using a pre-determined threshold of benefit or success. Percent improvement thresholds yield complementary information to continuous scale data for interpreting a clinical outcome. For example, a 20-point improvement (on a 100-point scale) may be a large or small percentage depending on the baseline starting point. Alternatively, a 20-point improvement may be clinically important regardless of whether the improvement threshold criterion is met. Also, a 50% improvement may be clinically important despite the magnitude of change in the outcome score. It should be noted that a shortcoming of threshold percent improvement is that it is ultimately somewhat arbitrary. Table 2 gives a cautionary tale showing how the choice of a 30% or 50% threshold for treatment success can lead to different results in terms of RD, NNT, and statistical significance. This in turn can impact conclusions on the clinical importance of the target intervention.
It is our opinion that the RD is preferable to the NNT as an outcome measure because of the difficulty in interpreting the 95% CI of the NNT. If RD = 10% (95% CI = -5%, 20%), then we can say that one in 10 participants treated will have successful outcomes attributable to the treatment compared to the control. This is equivalent to saying it will take treating 10 participants to get one better (NNT = 10). The 95% confidence interval for the RD can be expressed as between one in 20 favoring the control (-5%) to one in four favoring the treatment (20%). The advantage of using the RD is that the confidence interval is easily interpretable: a small benefit favoring the comparison intervention to a sizable advantage for the index treatment. A value of zero clearly shows no difference between groups. There is no need to confront the perplexing 95% confidence interval of the NNT: 1) the inclusion of ± ∞ when results are not statistically significant and 2) confidence limits that get smaller in magnitude the further away they are from the null.
Expected improvement graphs (Figure 2) can be a most useful tool for the practicing clinician. Most importantly, they can be used for prognosis. Both participants and clinicians can see the chance of achieving different levels of improvement and form realistic expectations of treatment outcomes. The graphs are also easier to interpret than a table of means and standard deviations. The improvement rates for the control group could be included to add the perspective of improvement relative to a sham, no intervention, or other therapy. We did not include the control group in our graphs for ease of interpretation.
Technical notes on analysis
Adjusted RD and adjusted NNT are recommended to take into consideration baseline differences between groups on important predictors of outcomes. This is especially important in small studies where imbalances in baseline characteristics are more likely to occur. Binomial regression is a generalized linear model that can compute differences between groups after adjusting for baseline covariates when the dependent variable (outcome) is a proportion; it assumes a binomial distribution for the outcome measure [29, 30]. The shortcoming of binomial regression is that it uses an iterative algorithm that must converge to an RD estimate. Often the model fails to converge or gives a poor estimate of the RD . One way to get around this is to run a logistic regression model to give an estimate of risk (probability of improvement in our study) for each individual. This risk can then be used to pre-specify the initial estimate of the mean for the dependent variable for the iterative process in binomial regression. This method was used for all our binomial regression analyses, because many models failed to converge without an initial estimate of the mean. In the two cases where the models still failed to converge, the following analysis was conducted.
An alternative analysis to binomial regression is ordinary least-squares multiple linear regression with the dependent variable coded as zero or one for the two values of the dichotomized outcome [31, 32]; this is also called modified least-squares regression when a robust standard error is used . The usual estimate of the difference between group means (grouping variable regression coefficient) turns out to be an estimate of the difference between group proportions as in binomial regression.
Odds ratios from logistic regression are commonly reported in epidemiological studies. In randomized trials, logistic and binomial regression can give different perspectives on outcomes. For example, consider two experiments were the RD = 40% - 20% = 20% in one and 10% - 5% = 5% in the other. The RD of the first is four times that of the second, but the odds ratios are similar, 2.67 and 2.1, respectively . Binomial regression is more difficult to use because of the convergence problem , but logistic regression cannot be readily used to compute the NNT.
The use of RD and NNT adjusted for baseline differences between groups in important determinants of outcomes is recommended for randomized trials with binary or dichotomized outcomes. The RD and its derivative the NNT are more clinician friendly than the odds ratios, and the RD in particular has an easier confidence interval to interpret than the NNT. Tabulation of the expected percentage of participants with successful care is a practical tool for the clinician.
Specifically in our study, spinal manipulation demonstrated a benefit in terms of a clinically important improvement of cervicogenic headache pain compared to a control when using a 30% and a 50% threshold for defining improvement. Our study demonstrated how results and interpretation may vary depending on the threshold chosen for dichotomizing continuous variables into binary outcomes.
This study was supported by the National Center for Complementary and Alternative Medicine, National Institutes of Health, Department of Health and Human Services (grant no. R21 AT002324, R25 AT002880, and K99 AT004196).
- Bender R: Calculating confidence intervals for the number needed to treat 12. Control Clin Trials. 2001, 22: 102-10. 10.1016/S0197-2456(00)00134-3.View ArticlePubMedGoogle Scholar
- Bolton JE: Sensitivity and specificity of outcome measures in patients with neck pain: detecting clinically significant improvement. Spine. 2004, 29: 2410-7. 10.1097/01.brs.0000143080.74061.25.View ArticlePubMedGoogle Scholar
- Schulz KF, Altman DG, Moher D: CONSORT 2010 Statement: updated guidelines for reporting parallel group randomised trials 7. BMC Med. 2010, 8: 18-10.1186/1741-7015-8-18.PubMed CentralView ArticlePubMedGoogle Scholar
- Nuovo J, Melnikow J, Chang D: Reporting number needed to treat and absolute risk reduction in randomized controlled trials. JAMA. 2002, 287: 2813-4. 10.1001/jama.287.21.2813.View ArticlePubMedGoogle Scholar
- Jaeschke R, Guyatt G, Shannon H, Walter S, Cook D, Heddle N: Basic statistics for clinicians: 3. Assessing the effects of treatment: measures of association. Can Med Assoc J. 1995, 152: 351-7.Google Scholar
- Guyatt G, Rennie D: Users' guides to the medical literature: a manual for evidence-based clinical practice. 2002, Chicago: American Medical AssociationGoogle Scholar
- Gordis L: Epidemiology. 2002, Philadelphia: W.B. Saunders Company, 2Google Scholar
- Ostelo RW, Deyo RA, Stratford P, Waddell G, Croft P, Von KM, Bouter LM, de Vet HC: Interpreting change scores for pain and functional status in low back pain: towards international consensus regarding minimal important change. Spine. 2008, 33: 90-4. 10.1097/BRS.0b013e31815e3a10.View ArticlePubMedGoogle Scholar
- Froud R, Eldridge S, Lall R, Underwood M: Estimating the number needed to treat from continuous outcomes in randomised controlled trials: methodological challenges and worked example using data from the UK Back Pain Exercise and Manipulation (BEAM) trial. BMC Med Res Methodol. 2009, 9: 35-10.1186/1471-2288-9-35.PubMed CentralView ArticlePubMedGoogle Scholar
- Fritz JM, Hebert J, Koppenhaver S, Parent E: Beyond minimally important change: defining a successful outcome of physical therapy for patients with low back pain. Spine. 2009, 34: 2803-9. 10.1097/BRS.0b013e3181ae2bd4.View ArticlePubMedGoogle Scholar
- Haas M, Spegman A, Peterson DH, Aickin M, Vavrek D: Dose-response and efficacy of spinal manipulation for chronic cervicogenic headache: a pilot randomized controlled trial. Spine J. 2010, 10: 117-28. 10.1016/j.spinee.2009.09.002. PMCID: PMC2819630PubMed CentralView ArticlePubMedGoogle Scholar
- Haas M, Aickin M, Vavrek D: A path analysis of expectancy and patient-provider encounter in an open-label randomized controlled trial of spinal manipulation for cervicogenic headache. J Manipulative Physiol Ther. 2010, 33: 5-13. 10.1016/j.jmpt.2009.11.007. PMCID: PMC2828362PubMed CentralView ArticlePubMedGoogle Scholar
- Vavrek D, Haas M, Peterson D: Physical exam and pain outcomes in a chronic headache study: what can we learn for outcome measures in the future?. J Manipulative Physiol Ther. 2010.Google Scholar
- International Headache Society: Classification and diagnostic criteria for headache disorders, cranial neuralgias, and facial pain. Cephalalgia. 1988, 8 (suppl 7): 1-96.Google Scholar
- Gatterman MI, Panzer DM: Disorders of the cervical spine. Chiropractic management of spine related disorders. Edited by: Gatterman MI. 1990, Baltimore: Williams & Wilkins, 205-55.Google Scholar
- Vernon H: Spinal manipulation and headaches: an update. Topics in Clinical Chiropractic. 1995, 2: 34-47.Google Scholar
- Souza TA: Differential diagnosis for the chiropractor: protocols and algorithms. 1998, Gaithersburg, MD: Aspen Publishers, Inc, 383-402.Google Scholar
- Peterson DH, Bergmann TF: Chiropractic technique: principles and practice. 2002, St. Louis: Mosby, 2Google Scholar
- Cooperstein R, Killinger L: Chiropractic techniques in the care of the geriatric patient. Chiropractic care of the older patient. Edited by: Gleberzon BJ. 2001, Boston: Butterworth-Heinemann, 359-83.Google Scholar
- Bergmann TF, Larson L: Manipulative care and older persons. Topics in Clinical Chiropractic. 1996, 3: 56-65.Google Scholar
- McDowell BL: Adjunctive procedures: physiological therapeutics. Chiropractic management of spine related disorders. Edited by: Gatterman MI. 1990, Baltimore: Williams & Wilkins, 330-78.Google Scholar
- Nicholson GG, Clendaniel RA: Manual Techniques. Physical Therapy. Edited by: Scully RM, Barnes MR. 1989, Philadelphia J.B. Lippincott Company, 926-85.Google Scholar
- Peterson DH, Bergmann TF: Chiropractic technique: principles and practice. 2002, St. Louis: Mosby, 2Google Scholar
- Nilsson N, Christensen HW, Hartvigsen J: The effect of spinal manipulation in the treatment of cervicogenic headache. J Manipulative Physiol Ther. 1997, 20: 326-30.PubMedGoogle Scholar
- Furlan AD, Brosseau L, Imamura M, Irvin E: Massage for low back pain: a systematic review within the framework of the Cochrane collaboration back review group. Spine. 2002, 27: 1896-910. 10.1097/00007632-200209010-00017.View ArticlePubMedGoogle Scholar
- Cherkin DC, Deyo RA, Sherman KJ, Hart G, Street JH, Hrbek A, Davis RB, Cramer E, Milliman B, Booker J, Mootz R, Barassi J, Kabin JR, Kuptchuk TJ, Eisenberg DM: Characteristics of licensed acupuncturists, chiropractors, massage thrapists and naturapthic physicians. J Am Board Fam Pract. 2002, 15: 463-72.PubMedGoogle Scholar
- Underwood MR, Barnett AG, Vickers MR: Evaluation of two time-specific back pain outcome measures. Spine. 1999, 24: 1104-12. 10.1097/00007632-199906010-00010.View ArticlePubMedGoogle Scholar
- User's manual: low back pain TyPE specification. Version 1. 1989, Bloomington, MN: Quality QuestGoogle Scholar
- StataCorp: Stata statistical software: release 11. 2009, College Station, TX: Stata CorporationGoogle Scholar
- McCullagh P, Nelder JS: Generalized Linear Models. 1969, New York: Chapman & Hall, 2Google Scholar
- Cheung YB: A modified least-squares regression approach to the estimation of risk difference. Am J Epidemiol. 2007, 166: 1337-44. 10.1093/aje/kwm223.View ArticlePubMedGoogle Scholar
- Lumley T, Diehr P, Emerson S, Chen L: The importance of the normality assumption in large public health data sets. Annu Rev Public Health. 2002, 23: 151-69. 10.1146/annurev.publhealth.23.100901.140546.View ArticlePubMedGoogle Scholar
- Sackett DL, Straus SE, Richardson WS, Rosenberg W, Haynes RB: Evidence-based medicine: How to practice and teach evidence-based medicine. 2000, Edinburgh: Churchill-Livingstone, 2Google Scholar
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