Wijeysundera DN, Austin PC, Beattie WS, Hux JE, Laupacis A. Outcomes and Processes of Care Related to Preoperative Medical Consultation. Arch Intern Med. 2010;170(15):1365–1374. doi:10.1001/archinternmed.2010.204
Copyright 2010 American Medical Association. All Rights Reserved. Applicable FARS/DFARS Restrictions Apply to Government Use.2010
Preoperative consultations by internal medicine physicians facilitate documentation of comorbid disease, optimization of medical conditions, risk stratification, and initiation of interventions intended to reduce risk. Nonetheless, the impact of these consultations, which may be performed by general internists or specialists, on outcomes is unclear.
We used population-based administrative databases to conduct a cohort study of patients 40 years or older who underwent major elective noncardiac surgery in Ontario, Canada, between 1994 and 2004. Propensity scores were used to assemble a matched-pairs cohort that reduced differences between patients who did and did not undergo preoperative consultation by general internists or specialists. The association of consultation with mortality and hospital stay was determined within this matched cohort. As a sensitivity analysis, we evaluated the association of consultation with an outcome for which no difference would be expected: postoperative wound infection.
Of 269 866 patients in the cohort, 38.8% (n = 104 695) underwent consultation. Within the matched cohort (n = 191 852), consultation was associated with increased 30-day mortality (relative risk [RR], 1.16; 95% confidence interval [CI], 1.07-1.25; number needed to harm, 516), 1-year mortality (1.08; 1.04-1.12; number needed to harm, 227), mean hospital stay (difference, 0.67 days; 0.59-0.76), preoperative testing, and preoperative pharmacologic interventions. Notably, consultation was not associated with any difference in postoperative wound infections (RR, 0.98; 95% CI, 0.95-1.02). These findings were stable across subgroups as well as sensitivity analyses that tested for unmeasured confounding.
Medical consultation before major elective noncardiac surgery is associated with increased mortality and hospital stay, as well as increases in preoperative pharmacologic interventions and testing. These findings highlight the need to better understand mechanisms by which consultation influences outcomes and to identify efficacious interventions to decrease perioperative risk.
Many of the 234 million people worldwide who undergo major surgery each year have medical comorbidities.1 For example, approximately 20% have diabetes mellitus,2 whereas 14% have chronic obstructive pulmonary disease.3 For such patients, preoperative consultations by internal medicine physicians (hereinafter referred to as preoperative medical consultations) present opportunities to better document comorbid disease, undertake risk stratification, optimize preexisting medical conditions, initiate interventions intended to decrease perioperative risk, and defer or cancel surgery, if necessary.
However, the impact of these consultations, which may be performed by either general internists or specialists (eg, cardiologists or endocrinologists), on outcomes is unclear. In a single-center cohort study of 1282 participants, perioperative medical consultation was associated with increased hospital stay and costs, but there was no significant difference in related processes of care, such as β-blockade.4 Conversely, a single-center randomized trial of 355 participants found that routine preoperative outpatient medical consultation reduced last-minute delays of surgery but had no significant effect on hospital stay or postoperative complications.5 Notably, 60% of patients in the control arm of this study underwent inpatient preoperative medical consultation after admission to the hospital. Given this paucity of information, we undertook a population-based cohort study in Ontario, Canada, to determine whether preoperative medical consultation was associated with reduced mortality and hospital stay after major elective noncardiac surgery.
After research ethics approval was received from Sunnybrook Health Sciences Centre, we used the following linked population-based administrative health care databases to undertake a retrospective cohort study in Ontario: the Canadian Institute for Health Information (CIHI) Discharge Abstract Database (hospital admissions), the Ontario Health Insurance Plan (OHIP) database (physician service claims), the Registered Persons Database (vital statistics), the Institute of Clinical Evaluative Sciences Physician Database (physicians' specialties), the Ontario Drug Benefit database (prescription medications for individuals older than 65 years), and the 2001 Canadian census. Although these databases lack physiologic and laboratory measures (eg, blood pressure and hemoglobin), they have been validated for many outcomes, exposures, and comorbidities.6- 9 During the study period, Ontario was Canada's most populous province, with more than 12 million residents who have universal access to physician and hospital services through a publicly funded health care program.
We retrospectively identified all Ontario residents older than 40 years who underwent the following elective surgical procedures between April 1, 1994, and March 31, 2004: abdominal aortic aneurysm repair, carotid endarterectomy, peripheral vascular bypass, total hip replacement, total knee replacement, large-bowel surgery, liver resection, Whipple procedure, pneumonectomy, pulmonary lobectomy, gastrectomy, esophagectomy, nephrectomy, or cystectomy. These procedures were selected because they are intermediate to high risk,10 applicable to either sex, and previously described in the CIHI database.11,12 Procedure codes in the CIHI database are very accurate.7,9
The principal exposure was preoperative medical consultation. Because no specific OHIP fee code identifies medical consultations for preoperative evaluation (as opposed to nonoperative indications), we used a validated claims-based definition: an OHIP claim for a consultation by a cardiologist, general internist, endocrinologist, geriatrician, or nephrologist within 4 months before surgery. In a multicenter cross-sectional study, this algorithm had a sensitivity of 90%, specificity of 92%, positive predictive value of 93%, and negative predictive value of 90% compared with re-abstraction of medical records.13
The outcomes of interest were postoperative mortality (30-day and 1-year), hospital stay, and in-hospital acute stroke. Mortality was determined by means of the CIHI database and Registered Persons Database, whereas the CIHI database was used to measure hospital stay. Although administrative data do not generally capture postoperative complications well,14 the CIHI database describes postadmission strokes with moderate accuracy (sensitivity, 73%; positive predictive value, 77%).7
Demographic information was obtained from the Registered Persons Database. We used validated algorithms to identify diabetes mellitus6 and hypertension.8 The OHIP database was used to identify patients who had previously required dialysis. Using the CIHI database, we identified other comorbidities on the basis of codes from the International Classification of Diseases (9th or 10th Revision) from hospitalizations within 2 years preceding surgery: ischemic heart disease, congestive heart failure, cerebrovascular disease, atrial fibrillation, aortic stenosis, mitral stenosis, peripheral vascular disease, pulmonary disease, chronic renal insufficiency, malignant disease, liver disease, rheumatologic disease, previous venous thromboembolism, and dementia.15- 17 The CIHI database was also used to identify previous mechanical aortic or mitral valve replacement procedures performed within 10 years preceding surgery. We used the OHIP database to identify outpatient anesthesia consultations18 and intraoperative invasive monitoring. Patients' socioeconomic status was estimated from their neighborhood median income in the 2001 Canadian census.
To understand how preoperative medical consultation might influence outcomes, we used the OHIP database to identify related processes of care: preoperative outpatient testing, preoperative cardiac interventions, postoperative admission to monitored beds, and postoperative mechanical ventilation. In addition, the Ontario Drug Benefit database was used to identify outpatient prescriptions (β-blockers, statins, warfarin sodium, and low-molecular-weight heparins) in patients older than 65 years.
Bivariate tests were initially used to compare patients who did and did not undergo preoperative medical consultation (t test, U test, χ2 test, Fisher exact test). A nonparsimonious multivariable logistic regression model was then developed to estimate a propensity score for consultation.19 Clinical significance guided the initial choice of covariates: age, sex, year, surgery, income quintile, hospital type (teaching, low-volume nonteaching, mid-volume nonteaching, high-volume nonteaching), comorbid disease, anesthesia consultation, and invasive monitoring. The following comorbid diseases were included in the model: ischemic heart disease, congestive heart failure, cerebrovascular disease, atrial fibrillation, aortic stenosis, valvular heart disease necessitating anticoagulation (mitral stenosis or mechanical aortic or mitral valve replacement), peripheral vascular disease, hypertension, diabetes mellitus, pulmonary disease, renal disease, rheumatologic disease, malignant disease, previous venous thromboembolism, and dementia. Previously described methods were used to categorize nonteaching hospitals into tertiles20 based on the annual volume of included procedures. A structured iterative approach was used to refine this model to achieve covariate balance within the matched pairs.21 Covariate balance was measured by means of the standardized difference, in which an absolute standardized difference greater than 10% represents meaningful imbalance.21 We matched consultation patients to no-consultation patients (without replacement) by means of a greedy-matching algorithm with a caliper width of 0.2 SD of the log odds of the propensity score. Continuous and dichotomous outcomes were then compared by statistical methods appropriate for paired data.21
Subgroup analyses were performed on the basis of sex, ischemic heart disease, diabetes mellitus, pulmonary disease, surgery, hospital type, concurrent anesthesia consultation, time, and perioperative cardiac risk as measured by the Revised Cardiac Risk Index.22 For these subgroup analyses, we repeated the same propensity-score matching process while simultaneously forcing an exact match on the subgroup characteristics. Conditional logistic regression was then used to assess for interactions between the exposure and specific subgroups. Because data on outpatient prescriptions in Ontario are available only for individuals older than 65 years and a 1-year look-back period was used to ascertain prior medication use, we performed an additional subgroup analysis among patients older than 66 years.
Several sensitivity analyses were also performed. First, we repeated the analyses after redefining the exposure with regard to the location where the consultation occurred (outpatient consultation only), type of physician who performed the consultation (general internist or specialist), and time between consultation and surgery (1-7 days, 8-60 days, or 61-120 days). In each case, comparisons were made against individuals who had not undergone preoperative medical consultation. Second, we assessed whether patients who underwent consultation had systematically different adherence to non–surgery-related preventive health measures (mammography, colonoscopy, and fecal occult blood testing). These analyses tested for unmeasured residual confounding. If patients who underwent consultation had systematically higher adherence, they may have been at lower risk for adverse outcomes (ie, healthy user bias); conversely, if they had lower adherence, they may have been at higher risk. Third, we measured the association of medical consultation with events that may be indicative of increased risk but are unlikely to be influenced by medical consultation, namely, epidural anesthesia (OHIP database)2 and in-hospital wound infection (CIHI database).23 These “tracer” analyses also tested for residual confounding. Specifically, we hypothesized that consultation would not be associated with increased rates of these events. Fourth, we tested the sensitivity of our findings to alternative matching methods, namely, exact matching on patient characteristics, exact matching on hospital characteristics, and matching on a modified propensity score. In the third matching scheme, the original propensity score was modified to include an estimate of unmeasured disease burden, namely, the number of hospital admissions within 2 years before surgery. Finally, we assessed the influence of an unmeasured binary confounder on the association between consultation and 30-day mortality.24
Analyses were performed with SAS, version 9.1 (SAS Institute Inc, Cary, North Carolina), and the R statistical programming language.25 A 2-tailed P value less than .05 was used to define statistical significance.
The study cohort consisted of 269 866 patients, of whom 38.8% (n = 104 695) underwent preoperative medical consultation (Table 1). Of these consultations, 94.2% (n = 98 583) were performed in outpatient settings. The median duration between consultation and surgery was 15 days (interquartile range, 8-31 days). Individuals who did and did not undergo consultation differed for all measured characteristics (Table 1).
Of patients who underwent consultation, 91.6% (n = 95 926) were matched to similar patients who did not. The covariate balance in the matched cohort was considerably improved (Table 2). Within this matched cohort, preoperative consultation was associated with higher rates of preoperative testing, preoperative use of β-blockers or statins (especially new use), and preoperative cardiac interventions (Table 3). Consultation was also associated with increased 30-day (relative risk [RR], 1.16; 95% confidence interval [CI], 1.07-1.25; P < .001) and 1-year (1.08; 1.04-1.12; P < .001) mortality (Table 3). These differences corresponded to numbers needed to harm of 516 (95% CI, 338-1089) at 30 days and 227 (155-426) at 1 year. Mean hospital stay was also longer in the consultation arm (9.07 days vs 8.39 days; difference, 0.67 days; 95% CI, 0.59-0.76; P < .001). The association of consultation with mortality was not influenced by any prespecified subgroup (Table 4).
Consultation was also associated with increased postoperative mechanical ventilation and admission to monitored beds, but no significant difference in acute stroke (Table 3). Nonetheless, in post hoc subgroup analyses, consultation was associated with a significantly increased risk of stroke after intra-abdominal or intrathoracic surgery (RR, 1.47; 95% CI, 1.14-1.89) but not after orthopedic or vascular surgery (interaction, P = .02) (eTable 1). These differences were mirrored by qualitatively similar variation (interaction, P < .001) in new β-blocker use (eTable 1). Specifically, in the setting of intra-abdominal or intrathoracic surgery, consultation was associated with relatively higher rates of both new β-blocker use and postoperative stroke (eTable 1). Within the first 30 days after hospital discharge, preoperative consultation was associated with reduced rates of prescriptions for warfarin and low-molecular-weight heparins (Table 3).
The sensitivity analyses generally suggested that any residual confounding within the matched cohort was not large. Consultation was not associated with differences in postoperative wound infections or adherence to screening mammography (Table 3). Notably, it was associated with increased adherence to colon cancer screening (which may be suggestive of healthier patients) and reduced rates of epidural anesthesia (which may be suggestive of lower perceived perioperative risk). The association of consultation with mortality was qualitatively unchanged when we redefined the exposure as outpatient consultations alone or used alternative matching processes (eTable 2). However, the association was increased in magnitude when the exposure was defined as consultations performed by specialists (cardiologist, endocrinologist, geriatrician, or nephrologist) or consultations performed within 1 to 7 days before surgery (eTable 2). An unmeasured confounder could render the association between consultation and 30-day mortality statistically nonsignificant but only if it at least doubled the odds of mortality and was present in 20% of patients who underwent consultation as compared with 10% of those who did not (Table 5).
In this population-based cohort study, preoperative medical consultation was associated with significant, albeit small, increases in mortality and hospital stay after major elective noncardiac surgery. These findings persisted despite extensive adjustments for confounders and were stable across a range of subgroups and sensitivity analyses. It was also evident that internists were actively guiding care as opposed to passively “clearing” patients for surgery. Specifically, consultation was associated with increases in related processes of care, such as specialized cardiac testing and β-blockade. However, the appropriateness of these interventions is debatable. For example, the Perioperative Ischemic Evaluation Study suggested that β-blockade, although previously recommended,10 may actually increase perioperative death and acute stroke.26 In addition, several commonly ordered tests, such as echocardiography and pulmonary function tests, are not generally recommended by consensus-based guidelines10,27 because they add little prognostic information.28,29
Given that the present study was observational in design, it is important to establish that the observed association between consultation and mortality was not entirely due to confounding by indication. Specifically, patients referred for consultation have more comorbid illness and are therefore at increased risk for adverse outcomes. Despite using statistical methods to adjust for these differences, our data sources might have lacked sufficient detail for adequate risk adjustment.
However, we conducted many sensitivity analyses that suggested that any residual confounding was not large. In tracer analyses, other indicators of higher risk (eg, wound infections and poor adherence to preventive health measures) were not increased in the consultation arm. Epidural anesthesia, which tends to be preferentially used in high-risk patients,2 was used less often in the consultation arm. In addition, previous studies using these same administrative data found that perioperative interventions that are preferentially used in higher-risk patients (eg, epidural anesthesia and anesthesia consultation)2,18 were nonetheless associated with benefit after risk adjustment. These previous results suggest that our data sources do contain sufficient information to adjust for confounding by indication. Our sensitivity analyses also suggest that an unmeasured binary confounder would have to be present in at least 20% of the consultation arm (as compared with 10% of the no-consultation arm) and be associated with high risk (odds ratio for 30-day mortality of ≥2.00) to render our findings statistically nonsignificant (Table 5). For comparison, congestive heart failure, a measurable major risk factor with an adjusted odds ratio of 2.1,30 is present in approximately 5% of patients.
Several factors may, in combination, explain why consultation was associated with slightly increased mortality. First, initiation of β-blocker therapy was significantly higher among patients who had undergone consultation. As described previously, this practice may have inadvertently led to increased mortality and stroke. Second, for reasons that are unclear, consultation was associated with decreased use of epidural anesthesia. This reduction may be important because systematic reviews31 and population-based studies2 have shown epidural anesthesia to be associated with improved postoperative survival. Third, consultation was associated with low rates of outpatient postoperative thromboprophylaxis, which were also significantly lower than those in the control arm. Unfortunately, our data sources do not contain information about thromboprophylaxis administered in the hospital; furthermore, administrative data do not accurately capture episodes of postoperative venous thromboembolism.32 The basis for these decreased rates is unclear and warrants further research. Potential explanations include internists' preference for shorter in- hospital courses of thromboprophylaxis or internists' postoperative discontinuation of long-term anticoagulant therapy that was previously initiated by patients' primary care providers.
In sensitivity analyses, the association of consultation with mortality was increased in magnitude when only consultations performed by specialists or within 1 to 7 days of surgery were considered. These findings should be viewed cautiously, especially given their widely overlapping confidence intervals with other definitions of preoperative medical consultation (eTable 2). Nonetheless, the findings are also plausible. For example, specialists, especially cardiologists, may be more aggressive in adhering to recommendations for perioperative β-blockade,33 thereby inadvertently increasing postoperative mortality.26 In addition, specialists may be more likely to focus on a narrow aspect of perioperative risk (eg, cardiac risk) rather than consider the wider spectrum for perioperative medical issues, such as pulmonary complications, thromboembolic episodes, and adequate glucose control. Consultations performed shortly before surgery would have afforded less time for preoperative optimization. They may have also provided little time for dose titration of β-blockade. Some authors have suggested that such β-blocker regimens are especially prone to adverse effects.34
The increased mortality associated with preoperative medical consultation in our study raises the question as to whether these consultations are required at all. We would caution against this interpretation. Compared with anesthesiologists and surgeons, internists are better trained to address medical problems in surgical patients, such as glucose control in diabetic patients or exacerbations of chronic obstructive pulmonary disease. In addition, our results demonstrate that internists are willing to actively participate in perioperative care. Specifically, we found that consultation was associated with significantly increased rates of perioperative interventions and testing. Despite this clear potential for consultation to improve outcomes, at least 2 major issues limit its effectiveness. There are limited data for consultants to refer to when determining which tests and interventions are actually helpful. For example, routine β-blockade had previously been recommended for any surgical patient with risk factors35 largely on the basis of 2 small randomized trials.36,37 As described earlier, this approach may instead have caused harm.26 In addition, some related processes of care can be improved. For example, the most common specialized test associated with consultation was echocardiography, despite the minimal prognostic information that it adds.28 In summary, our findings should not be interpreted as a justification for abandoning preoperative consultation but rather as a stimulus to examine it more closely and conduct more high-quality research to establish which aspects of perioperative care do more good than harm.
Our study has several limitations. First, as an observational study, our results demonstrate an association between consultations and outcomes but do not prove causation. Similar cohort studies using different samples of surgical patients are therefore needed to confirm our findings. However, alternative study designs also have limitations. Randomized trials, although better suited to proving causality, are likely unfeasible. Many surgeons would simply not permit older patients with comorbid disease to be randomized to the no-consultation arm.
Second, the increase in mortality associated with consultation, albeit statistically significant, was small. Specifically, the numbers needed to harm were 516 at 30 days and 227 at 1 year. Nonetheless, the criterion by which consultation should be judged, especially when administered to almost 40% of patients in the cohort, is whether it reduces mortality. On the basis of multiple sensitivity analyses, our results suggest that, even if some residual confounding was present, consultation was unlikely to have conferred a major benefit.
Third, our data sources cannot account for patients who had their surgery canceled after being deemed unfit for surgery by the consulting internist. Nonetheless, such cancellations are very rare, occurring after approximately 1% to 2% of preoperative consultations.38,39
Fourth, the estimated associations between consultation and outcomes are valid for the matched cohort but not necessarily for unmatched individuals. Unmatched individuals who underwent consultation had very high perioperative risks, based on significant burdens of comorbid disease, and risks of 30-day mortality that were double that of the matched cohort (eTable 3). Thus, the absence of benefits from consultation may not be generalizable to such very-high-risk surgical patients. However, these unmatched patients represented only 8.4% of individuals who underwent preoperative medical consultation.
Fifth, our cohort only included elective intermediate- to high-risk surgeries. Nonetheless, urgent or emergent procedures are unlikely to be delayed to facilitate preoperative consultation. In addition, patients undergoing low-risk ambulatory surgery are at very low risk of major complications40 and unlikely to benefit from consultation.
Finally, administrative data sources do not adequately capture some postoperative complications (eg, myocardial infarction),14 causes of death, detailed clinical information, and in-hospital processes of care (eg, inpatient medications). Such information may help to better describe how consultation can alter outcomes. Future multicenter studies of preoperative consultation should therefore include more detailed measurements of these processes of care.
Our study warrants comparison with a single-center cohort study that evaluated outcomes associated with perioperative medical consultation.4 These previous results mirror our own in that consultation was associated with increased hospital stay and a trend toward increased complications. Conversely, the investigators did not find any significant differences in related processes of care, such as β-blockade or glucose control. Nonetheless, these findings may be explained by limited statistical power and the investigators' definition of perioperative consultation. Specifically, the exposure was defined as any consultation within 1 day of surgery,4 thereby excluding cases in which patients were seen days to weeks before surgery to help facilitate preoperative risk stratification and optimization.
Our findings suggest 2 broad areas for research in perioperative medicine. As noted earlier, similar multicenter cohort studies should be conducted with other datasets to confirm our findings in Ontario. Where possible, these studies should include detailed information on outpatient and inpatient processes of care to better understand the mechanisms by which consultation influences outcomes. In addition, our findings emphasize the need for more high-quality research to identify efficacious approaches for decreasing perioperative risk. In the absence of such data, consultants have only limited avenues for improving the outcomes of surgical patients.
In conclusion, in this analysis of administrative databases, preoperative medical consultation was associated with increased mortality and hospital stay after major elective noncardiac surgery, as well as with increases in preoperative pharmacologic interventions and testing. These findings were stable across a range of subgroups and sensitivity analyses. Further research is needed to confirm our findings in different populations, define mechanisms by which consultation influences outcomes, and identify efficacious interventions to decrease perioperative risk.
Correspondence: Duminda N. Wijeysundera, MD, Department of Anesthesia, Toronto General Hospital and University of Toronto, EN 3-450, 200 Elizabeth St, Toronto, ON M5G 2C4, Canada (firstname.lastname@example.org).
Accepted for Publication: January 25, 2010.
Author Contributions: Dr Wijeysundera had full access to all the data in the study and takes responsibility for the integrity of the data and the accuracy of the data analysis. Study concept and design: Wijeysundera, Beattie, Hux, and Laupacis. Acquisition of data: Wijeysundera and Beattie. Analysis and interpretation of data: Wijeysundera, Austin, and Beattie. Drafting of the manuscript: Wijeysundera. Critical revision of the manuscript for important intellectual content: Wijeysundera, Austin, Beattie, Hux, and Laupacis. Statistical analysis: Wijeysundera and Austin. Obtained funding: Wijeysundera and Beattie. Administrative, technical, and material support: Laupacis. Study supervision: Beattie and Laupacis.
Financial Disclosure: None reported.
Funding/Support: Dr Wijeysundera is supported in part by a Clinician-Scientist Award from the Canadian Institutes of Health Research. Drs Wijeysundera and Beattie are supported in part by Merit Awards from the Department of Anesthesia at the University of Toronto. Dr Austin is supported in part by a Career Investigator Award from the Heart and Stroke Foundation of Ontario. Dr Beattie is the R. Fraser Elliot Chair of Cardiac Anesthesia at the University Health Network. This study was supported in part by the Institute for Clinical Evaluative Sciences and the endowment fund of the R. Fraser Elliot Chair of Cardiac Anesthesia at the University Health Network. The Institute for Clinical Evaluative Sciences is supported in part by a grant from the Ontario Ministry of Health and Long-term Care.
Disclaimer: The sponsors had no role in the design and conduct of the study; in the collection, analysis, and interpretation of the data; or in the preparation, review, or approval of the manuscript. The opinions, results, and conclusions are those of the authors, and no endorsement by the Ontario Ministry of Health and Long-term Care or the Institute for Clinical Evaluative Sciences is intended or should be inferred.
Additional Contributions: Arthur Slutsky, MASc, MD, FRCPC, Muhammad Mamdani, PharmD, MA, MPH, and Chaim M. Bell, MD, PhD, FRCPC, provided helpful comments on earlier versions of the manuscript.