Objective To improve medication appropriateness and adherence in elderly patients with multimorbidity, we developed a complex intervention involving general practitioners (GPs) and their healthcare assistants (HCA). In accordance with the Medical Research Council guidance on developing and evaluating complex interventions, we prepared for the main study by testing the feasibility of the intervention and study design in a cluster randomised pilot study.
Setting 20 general practices in Hesse, Germany.
Participants 100 cognitively intact patients ≥65 years with ≥3 chronic conditions, ≥5 chronic prescriptions and capable of participating in telephone interviews; 94 patients completed the study.
Intervention The HCA conducted a checklist-based interview with patients on medication-related problems and reconciled their medications. Assisted by a computerised decision-support system (CDSS), the GPs discussed medication intake with patients and adjusted their medication regimens. The control group continued with usual care.
Outcome measures Feasibility of the intervention and required time were assessed for GPs, HCAs and patients using mixed methods (questionnaires, interviews and case vignettes after completion of the study). The feasibility of the study was assessed concerning success of achieving recruitment targets, balancing cluster sizes and minimising drop-out rates. Exploratory outcomes included the medication appropriateness index (MAI), quality of life, functional status and adherence-related measures. MAI was evaluated blinded to group assignment, and intra-rater/inter-rater reliability was assessed for a subsample of prescriptions.
Results 10 practices were randomised and analysed per group. GPs/HCAs were satisfied with the interventions despite the time required (35/45 min/patient). In case vignettes, GPs/HCAs needed help using the CDSS. The study made no patients feel uneasy. Intra-rater/inter-rater reliability for MAI was excellent. Inclusion criteria were challenging and potentially inadequate, and should therefore be adjusted. Outcome measures on pain, functionality and self-reported adherence were unfeasible due to frequent missing values, an incorrect manual or potentially invalid results.
Conclusions Intervention and trial design were feasible. The pilot study revealed important limitations that influenced the design and conduct of the main study, thus highlighting the value of piloting complex interventions.
Trial registration number ISRCTN99691973; Results.
- complex intervention
- drug therapy, computer-assisted
- medication adherence
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- complex intervention
- drug therapy, computer-assisted
- medication adherence
Strengths and limitations of this study
This is the first randomised piloting of a complex intervention addressing polypharmacy in primary care.
The studied complex intervention aims to support an interaction assessment, discover patient preferences and use a computerised decision-support system (AiDKlinik) to prioritise polypharmacy.
The complex intervention addressed the entire medication use process and included a health care assistant of the general practice to empower patients and to reduce physician's workload.
The pilot study design allowed critical procedures to be implemented and all materials and instruments for the planned main study on the effectiveness of the complex intervention to be tested.
The pilot study design demanded considerable effort and doubled the sample size for the feasibility testing of the complex intervention.
Currently, as many as 80% of consultations in primary care involve patients with multiple chronic conditions.1 Multiple disorders in patients are likely to result in the prescription of a number of different drugs and often in polypharmacy (>4 drugs). Polypharmacy is associated with drug underuse, particularly in older people,2 ,3 and also poses a substantial risk for adverse drug reactions (ADR) and non-adherence, possibly leading to hospitalisation, cognitive impairment, falls, increased mortality and an increase in healthcare costs.4–7 About 60% of drug-related hospitalisations are due to inappropriate prescriptions, and about 20% to non-adherence.8 ,9 At least half of these are preventable.10 ,11
Although interventions of proven effectiveness on clinical outcomes are still lacking,12 ,13 promising strategies aimed at combating inappropriate polypharmacy exist. A first essential step is to get a comprehensive overview of the patient's current medication and intake habits. This can be accomplished by means of a so-called ‘brown bag review’, in which patients are invited to bring all their medicines to the practice in their original packaging.14 Concurrently, patient adherence and hitherto unknown prescriptions from other healthcare providers can be assessed.15 ,16 This information is necessary if prescribing is to be improved.17–19 Second, the use of computerised decision support systems (CDSS) can help ensure appropriate prescribing.20–23 Third, preconsultation interviews provide an opportunity for healthcare assistants (HCAs) to encourage older patients to tell their physicians about any medication-related problems, thus improving adherence.24
On the basis of these strategies, we designed a complex intervention to improve prescribing and adherence in older patients with multimorbidity and polypharmacy in general practice in Germany. We also included HCAs from the participating practices. HCAs receive less training in patient care than nurses and are comparable to certiﬁed medical assistants in the USA with regard to education, responsibilities and remuneration.25 ,26 HCAs have been repeatedly and successfully included in chronic care interventions in Germany: under the supervision of general practitioners (GPs), they have followed evidence-based protocols and algorithms with fixed interview questions, and have provided self-management support or telephone monitoring for conditions such as osteoarthritis, major depression and chronic heart failure.27–29
We tested the feasibility of the intervention in a cluster-randomised controlled pilot study.30 To improve the study design of the main study, we focused on aspects relating to the recruitment of practices and patients, randomisation procedures, prevention of dropouts and outcome measures that are relevant for subsequent sample size calculations for the main study.31 ,32
Design and participants
We performed a cluster-randomised, controlled pilot study with the general practice as the unit of randomisation. We compared a complex intervention (intervention group) with usual care (control group) with an allocation ratio of 1:1. Treatment allocation was concealed to practices and patients until data collection at baseline had been completed (figure 133–58).
We invited academic teaching practices and GPs who attended the Frankfurt General Practice Day to participate in the study. Inclusion criteria for practices were the provision of primary care within the German statutory health insurance system and that the HCA could access the internet. A random sample of patients (for patient recruitment, see figure 1, icons c-e) fulfilling the following criteria was included: age ≥65 years, ≥3 chronic conditions, ≥5 chronic prescriptions, ≥1 practice visit during the past quarter and the ability to fill in questionnaires and participate in telephone interviews. We excluded patients with cognitive impairment (Mini-Mental Status Examination, MMSE <26),36 because we designed our intervention for cognitively intact patients and did not address caregivers. Further exclusion criteria were a life expectancy ≤6 months, alcohol and drug abuse (based on the GP's assessment).
Intervention and control treatment
The PaTplot59 (figure 1) shows the elements of the complex intervention. It consists of a brown bag review and a checklist-based preconsultation interview with the patient that is conducted by the HCA (see online supplementary web–appendix 1), a computer-assisted medication review carried out by the GP and a GP-patient consultation. GPs in the intervention group received practice guidelines for older patients,35 and the complex intervention was implemented at their practice on a single occasion.
GPs in the control group also received the practice guidelines for older patients,35 but continued with usual care.
Feasibility of the study
The pilot study aimed to test all procedures, materials and instruments for their suitability for use in the main study.31 ,32 The achievement of recruitment targets, the balance of cluster sizes, treatment allocation and baseline characteristics in both groups, and reasons for non-participation and loss to follow-up of patients were examined.
Feasibility of outcome measures
Medication appropriateness index (MAI): As a potential primary outcome to be used in the main study, we tested the MAI, because it is widely accepted that it focuses on patients rather than drugs and diseases.60 This fitted in well with our holistic intervention which was aimed more at optimising medication prescriptions than on reducing the number of prescriptions per se. The MAI consists of 10 items: (1) indication for the drug, (2) efficacy for the condition, (3) correctness of dosage, (4) correctness of directions, (5) practicality of the directions, (6) drug–drug interactions, (7) drug-disease interactions, (8) unnecessary drug duplications, (9) correctness of treatment duration and (10) cost.61 ,62 Item (10) was omitted because variable discount contracts between pharmaceutical and statutory health insurers preclude cost comparisons in Germany. Items (1) to (9) were rated for each prescription on a three-point Likert scale (‘1’ represented appropriateness, ‘3’ inappropriateness and ‘2’ a middle rating of hardly appropriate). Operational definitions and explicit instructions were determined a priori for each index item. An experienced clinical pharmacologist (SH) coded the MAI following a blinded chart review based on the GP's prescriptions, multimorbidity (diagnoses, Cumulative Illness Rating Scale—CIRS)33 ,34 (figure 1, icon f) and ADR symptoms (figure 1, icon h). MAI ratings were transformed by subtracting 1 from the original rating, resulting in values ranging from ‘0’ (best rating) to ‘2’ (worst rating), and adding them up to give an MAI score ranging from 0 to 18 per prescription. MAI sum scores across the entire medication regimen of the patient were calculated and the differences in the MAI sum scores between baseline (T0) and T1 (T1-T0) resp. T2 (T2-T0) were determined with lower MAI scores denoting better prescribing appropriateness. A negative value for T1-T0 or T2-T0 therefore reflected an improvement in prescribing quality. Reliability of the MAI: 6 months after T2, the clinical pharmacologist (SH) received a sample of medication reviews for a second rating (blinded to the results of the first) to determine intra-rater reliability. To explore the benefit of a second independent MAI rating, another experienced clinical pharmacologist, blinded to the results of SH, reviewed the same sample to test inter-rater reliability. The sample was randomly drawn from T1 data until the prespecified sample size was achieved.
We also examined health-related quality of life (EQ-5D index),37 functional status (WHO Disability Assessment Schedule, WHO-DAS II),38 adherence and related measures, as these are secondary outcomes that may be used in the main trial. We collected data on self-reported adherence according to Morisky (four items resulting in sum scores of 0–4 points, with low scores indicating good adherence) and the Medication Adherence Rating Scale (MARS; five items resulting in sum scores of 5–25 points, with high scores indicating good adherence).40 ,42 We also measured the discrepancy between medicines actually taken (reported at patient's interviews) and medicines prescribed (reported by GP). According to Barat et al,63 we calculated (1) the drug score (DS=number of drugs reported by the patients/number of drugs reported by the GP), (2) the dose score (DoS=d1(a1)+d2(a2)+d3(a3)+…/n, where di is the drug used by the patients (value 0 or 1), n is the number of drugs in the GP’s report, and ai is the dose-deviation rate calculated by dividing the patient's reported daily dose with the daily dose reported by the GP) and (3) the regimen score (RS=d1(b1)+d2(b2)+d3(b3)+…/n, where bi is the regimen-deviation rate calculated by dividing the patient's reported daily intake frequency (once daily, twice daily, etc.) with the corresponding frequency reported by the GP). Scores outside an interval of 0.8–1.2 were considered to be divergent.63 Adherence-related measures were complexity of medication (total number of prescriptions, number of single doses/day, Medication Regimen Complexity Index, MRCI)64 and Beliefs about Medicines Questionnaire.41 In proxy of under-treatment, pain intensity was measured by means of a single visual rating scale (VRS). The numbers of days in hospital, deaths and symptoms of side effects were analysed. We determined the differences between baseline (T0) and T1 (T0-T1) resp. T2 (T0-T2).
Feasibility of the intervention
We used mixed methods consisting of brief questionnaires, semistructured interviews and case vignettes (figure 1, icons l-o and 6–10; online supplementary web–appendix 2). All interviews were audio taped, transcribed and analysed according to qualitative description and content analysis techniques:65 ,66 The answers were coded by two independent researchers and dissent was resolved by discussion. Results were analysed according to a previously designed coding scheme and rated as ‘feasible’, ‘not feasible’ and ‘feasible with limitations’.67 For the analysis of the case vignettes, need for technical support with the CDSS was categorised (none, minor—help was needed to execute a specific procedure and major—help was needed with necessary operations). GPs' case vignettes were also analysed for the number of CDSS modules used and reduction in the number of drugs and inappropriate prescriptions.
Estimations of sample sizes
According to earlier suggestions that 30 patients per group would allow a good estimate of mean and SD,31 ,68 we aimed to recruit at least 50 patients for each of the control and intervention groups, resulting in an overall sample size of N=100. With a target size of 5 patients per cluster, we needed to recruit 10 GP practices per group. This sample size also allowed the estimation of the intracluster correlation coefficient (ICC) that would be required to support the sample size calculation for the main study.
Inter-rater reliability in the MAI assessment ranged from 0.47 to 0.99, and intra-rater reliability from 0.70 to 0.96.61 ,62 ,69–73 Since a less than moderate κ would be inacceptable in our trial, we assumed the null hypothesis value to be 0.4. With an estimated proportion of 0.3 positive ratings, a two-tailed test and 90% power, we therefore needed N=255 prescriptions to detect a κ of 0.6 (95% CI 0.5 to 0.7).74 ,75
For all outcomes, the primary analysis took place according to the intention-to-treat principle. The primary comparison between the intervention and control groups was made on the basis of the difference between MAI scores at baseline (T0) and 6 weeks after the beginning of the intervention (T1). Descriptive statistics and ICCs are provided for the baseline characteristics of practices and patients, as well as for the primary and secondary outcome measures. To analyse the differences between the intervention and control groups, linear mixed models were used. The results are presented as adjusted (for clustering) mean differences between groups with 95% CIs and p values, and the corresponding ICCs. Since this was a pilot study, the analysis of all result parameters remained primarily descriptive.
To determine the reliability of the MAI, the individual ratings were dichotomised into two groups, ‘appropriate’ versus ‘inappropriate’, in accordance with earlier suggestions: (1) the ratings ‘1’ and ‘2’ were considered to be ‘appropriate’ and ‘3’ ‘inappropriate’,62 ,76 (2) prescriptions rated as ‘1’ were considered ‘appropriate’ and those rated as ‘2’ or ‘3’ ‘inappropriate’.71 Observer agreement and chance-adjusted agreement were calculated using κ-statistics, and alternative measures, such as the B-statistic and prevalence-adjusted bias-adjusted κ (PABAK), when the prevalence of positive ratings was low.77–79
Feasibility of the study
Recruitment and maintenance
Of the 692 potentially eligible patients from 20 general practices, 230 were selected at random and 100 were included (flow chart: online supplementary web–appendix 3). Of the 130 patients not included in the study, 67 were not invited because the recruitment target had already been reached, 41 did not meet the inclusion criteria, 20 refused to participate and 2 gave no reasons. In the intervention group, one patient at T1 (hospitalised) and four patients at T2 (three were hospitalised, one refused further participation) were lost to follow-up. In the control group, we lost two patients at T1 and subsequently at T2 (one died, one switched GP).
The GPs were mostly male (75%), had a median age of 57 years (range: 40–62 years) and were clinically experienced (on average 22 years). The median age of the HCAs was 42 years (20–58 years), and of the patients 75 years (64–93 years). The baseline characteristics of the study population are shown in table 1.
At baseline, the outcome measures were balanced in both groups (table 2). Medication appropriateness: The vast majority of MAI ratings was ‘appropriate’ (see online supplementary web–appendix 4) and changes in mean MAI scores were small in both groups (table 3). Based on B-statistics, the intra-rater reliability for the MAI items ranged from 0.90 to 0.99, and inter-rater reliability from 0.83 to 0.94 (see online supplementary web–appendix 4). Mean differences in secondary outcomes between groups were small with wide two-sided 95% CIs. There was also no consistent trend across measures (table 4). Completeness of data: Outcome measures based on data from case report forms and patient telephone interviews including the MAI could be analysed almost completely. The proportion of missing values in secondary outcomes based on data from patient questionnaires ranged from 5% to 10% at baseline, 6% to 11% at T1 and 10% to 14% at T2. The VRS had the highest number of missing values (table 4).
Feasibility of the intervention
Perspective of GPs
In short questionnaires (figure 1, icon l), GPs reported a median time requirement of 35 min (IQR: 25—60′) per patient and that they were very satisfied or satisfied with 39/49 (80%) interventions, rather satisfied with 7/49 interventions (14%) and rather dissatisfied with 1/49 interventions (2%). Two interventions were not assessed. In semistructured interviews, 10 GPs (figure 1, icon 7) described the intervention as feasible or feasible with limitations: 9/10 reported positive experiences using the CDSS (‘it is clearly structured, it is well-arranged’; ‘I liked … the weightings (for alerts)’), 1/10 did not (‘I did not feel comfortable with this programme…because I did not completely understand it’.). Five of 10 GPs reported that the GP–patient consultation was a positive experience (‘clearly more systematic than regular consultations’; ‘more often focused on adverse effects’; ‘cooperation with patients has been improved’) and 9/10 GPs experienced improved communication with HCAs (‘I certainly talked more with the HCA about one or the other patient … because she wanted to give her feedback’).
With the case vignettes (figure 1, icon 8), 7/10 GPs needed support in using the CDSS (support with a specific command: 5/7, major support: 2/7). To optimise medication for the case vignette, GPs used on average two of the four available CDSS alert functions (figure 1, icon 4). The number of prescriptions fell by 58%, potentially severe drug–drug interactions by 86% and inappropriate renal dosage adjustments by 71%. Inappropriate non-steroidal anti-inflammatory drugs prescriptions for the case vignette were stopped by 6/10 GPs and substituted with appropriate analgesics by 3/10 GPs. The technical usability of the CDSS (figure 1, icon n) was rated by GPs in median with ‘good’ for learnability (IQR: 1.25–2), clarity (1–2) and handling (2–2.75). The technical usability of the CDSS in everyday practice was assessed in median 4.5 (IQR 2.25–5) and GPs reported in interviews that the ‘poor’ rating was mainly due to a lack of connectivity with their practice software systems and the amount of time required.
Perspective of HCAs
In short questionnaires (figure 1, icon m), HCAs reported a median time requirement of 45 min (IQR: 33—70′) and were very satisfied or satisfied in 92% of cases (45/49), and rather satisfied in 2/49 cases (4%). No intervention was considered rather dissatisfying or worse, and two interventions were not assessed. In semistructured interviews, HCAs (figure 1, icon 9) reported no major problems with the intervention and positive experiences with the patients: 9/10 HCAs had no difficulties using and filling out the MediMoL (‘I really had no problems, it all went well’), one had difficulties (‘Not all the questions were clear to me’). The CDSS performed well: 9/10 HCAs described the experience as ‘very good’ (‘I could use it very easily, I am doing fine with it’), one considered the experience ‘rather good’ (‘It would be nice, if (the CDSS) would transfer (the medication) …from Medibox 1 to Medibox 2’). The HCAs felt the investigator and intervention trainings (figure 1, icons 1 and 2) prepared them well for the study (‘The tasks were clearly described and well-structured; I had no problems’). The encounter with the patient was assessed particularly positively (‘I really liked being allowed to do the tests on the patients and being able to work so closely with them’).
The case vignette (figure 1, icon 10) was understood by 6/10 HCAs without any help, while 4/10 HCAs needed minor support (eg, to enter the name of a complementary drug formulation in Medibox 2). The technical usability of the CDSS (figure 1, icon o) was rated by the 10 HCAs in median with ‘good’ for all dimensions, with the IQR regarded as slightly better for learnability and handling (1.25–2) than for clarity and workaday practicability (2–2).
In telephone interviews, 23/42 patients knew what the study was about and explained the potential benefits for themselves (‘Drug tolerance and interactions between different drugs are looked at, to see if there might be one that could be left out’), whereas the remaining patients did not understand the study and did not feel they had benefited from participating in it (‘I'm not reckoning on benefiting from it personally, but my doctor asked me to’). None of the patients said that any of the questions asked by the HCA in the preconsultation interview had made them feel uneasy. Patients' symptoms were mostly about the study methods (‘Being asked twice about medicines; only one of mine was dropped; that could have been decided quicker’; ‘It's difficult to answer all the questions in the questionnaire with a simple yes or no’).
The complex intervention to prioritise and optimise multimedication in older patients with multimorbidity, and the study design, are feasible in a general practice setting. However, the pilot study revealed a number of limitations and potential barriers to the future implementation of the complex intervention that should be addressed when designing the main trial.
Feasibility of the complex intervention
Participating GPs valued the structured systematic approach to conducting consultations and said working relationships with patients and HCAs had improved. HCAs appreciated being involved in the complex intervention. Both GPs and HCAs reported mainly positive experiences with the tools MediMoL and the CDSS and rated the (technical) usability of the CDSS as ‘good’. Moreover, GPs were often surprised by the discrepancy between prescribed and taken medicines, as confirmed by the brown bag review. Only slightly more than half the study patients were fully aware of the rationale and the aims of the study. However, informed patients welcomed the chance to detect inappropriate prescriptions and to adjust their medication. Nevertheless, GPs pointed out that the process required considerable time and said the incompatibility of the CDSS with their practice software was a relevant barrier to future practice implementation. Positive results in interviews and questionnaires differed somewhat from the situation with case vignettes where difficulties were experienced using the CDSS application: more GPs than HCAs needed help in using the features and running the programme. Most HCAs and GPs did not use the CDSS following the completion of the final intervention, so their difficulties may have resulted from a lack of training and the time lag between the final intervention and the case vignette (figure 1). Since we did not provide a manual, it is possible that not all practices correctly implemented the CDSS.
Feasibility of the trial design
Most procedures went well—recruitment was completed with equal cluster sizes, randomisation resulted in overall balanced groups, loss to follow-up was within acceptable limits and data collection and the medication reviews by the clinical pharmacologist were feasible. Missing data were most common in patients' questionnaires, and in the VRS in particular. Patients' interviews showed that some patients had difficulties understanding questions from the validated instruments. The most relevant outcome measures, MAI and EQ-5D, showed an almost perfect baseline value, leaving little room for improvement. First, cardiovascular comorbidity was highly prevalent, with common diseases sharing the same pathways and treatment targets. This may have prevented GPs from having to deal with potentially harmful interactions. Second, a reduction in inappropriate prescriptions was observed in both groups, indicating a likely contamination effect in the control group: both groups received the study protocol including a detailed description of the intervention. Although the CDSS was only available to the intervention group, the control group may have conducted brown bag reviews and medication reviews with or without computer support. Some practice software provides alert features for drug–drug interactions. However, these are often deactivated due to over-alerting.80
Furthermore, the low prevalence of ‘inappropriate prescriptions’ and imbalanced marginals for MAI ratings in our sample led to paradoxically low κ values despite high intra-rater and inter-rater observer agreement.79 In this situation, alternative reliability measures such as B-statistics and PABAK are recommended.77–79 Using these measures, intra-rater reliability of MAI ratings showed almost perfect agreement81 and intra-rater reliability was slightly better, which is in line with former observations.62 ,69 ,73 Evaluated secondary outcomes showed small changes but supported for most of them a further use in the main study (EQ-5D and adherence-related measures such as medication complexity). As observed in earlier studies,82 measures of self-reported adherence did not appear to provide valid results, as they contradicted results from comparisons of prescribed with taken medicines, and showed ceiling versus floor effects. Additionally, MARS had a large number of missing values. The functionality outcome (WHO-DAS II) was not usable, because the manual was under development and did not provide a correct formula.
The application of the cluster-RCT design was both a strength, because it allowed to put in place all procedures of the planned main study, and a challenge, because the integration of a control group doubled the sample size for feasibility testing of the complex intervention. Furthermore, participants may have overestimated the time required by the intervention because the time required for data collection and other procedures may have been included in estimates of the time required to perform the complex intervention. With the use of mixed methods, however, we were able to identify obstacles to the complex intervention and its implementation that helped us to improve the design of the main study. The CDSS recorded data on use (eg, date of use, completion of Mediboxes by GPs/HCAs), but these data did not provide information on whether or not the users correctly applied the different features to check for interactions, appropriate dosage, etc. In qualitative interviews, GPs and HCAs did not report problems using the CDSS when asked. However, case vignettes helped detect difficulties experienced by GPs and HCAs in the use of the new software. These can be eliminated by intensifying training and providing supporting material. Limited resources prevented us from gaining detailed insights into usual care provided by GPs when adjusting medication for older multimorbid patients, and this is a further limitation of our study. This information could have been helpful in planning the main trial.
This article provides the results of the systematic piloting of a complex intervention for polypharmacy and its corresponding trial design in primary care. Published trials on complex interventions in polypharmacy included in a current Cochrane review were not piloted at all or mentioned only a piloting phase without describing results and conclusions.12 Many of the studies were conducted after publication of the MRC guidance that strongly recommends a piloting phase.30 ,83 Very recently, Clyne and coauthors reported on an alternative approach, also aimed at helping in the development of a complex intervention to reduce potentially inappropriate prescribing (PIP), but which uses explicit criteria.84 The authors described an exhaustive consensus process for deriving an acceptable set of PIPs from lists identified in a literature review (eg, Beers and STOPP criteria85 ,86). Focusing on a high acceptability at the provider level, the authors applied predominantly qualitative methods that resulted in the stepwise improvement of the intervention. Our approaches differed mainly in purpose, methods and (presumably) in cost but both highlight the fact that descriptions of piloting phases are particularly useful for a number of reasons: they typically use more diverse techniques than full studies, uncover critical pitfalls and challenges and provide important insights into promising techniques, facilitators and barriers and often also into the causes of success and failure.
Feasibility testing of our complex intervention has enabled us to improve the design of the main study: as a consequence, investigator training has been intensified and supported by a written manual with a strong focus on using the CDSS. The multitude of used interfaces will prevent significant improvement in connectivity to practice software systems in the main study. The National Association of Statutory Health Insurance Physicians has only recently begun to work on harmonising data interfaces for manufacturers of practice software, thus facilitating future data exchange with systems such as our CDSS.
Feasibility testing identified a potential contamination problem with the control group. We have therefore decided that in the main study, no details of the intervention will be shared with healthcare professionals of the control group. Furthermore, we have changed the inclusion criteria. To include a greater number of patients at risk of (manageable) interactions, patients have to have not only three or more chronic diseases, but the diseases must be from at least two different chapters of ICD-10. We have also replaced impractical outcome measures (VRS, WHO-DAS II and MARS).
Although we have demonstrated feasibility and potential limitations of the complex intervention, its effectiveness in general practice has yet to be proven. Furthermore, it is as yet unclear whether the advantages will outweigh the disadvantages in terms of required time and costs, and whether the barriers to a wider implementation in routine care can be removed.
Our pilot study of a complex intervention to prioritise and optimise multimedication in older patients with multimorbidity has confirmed the feasibility of the intervention and the study design, but has also revealed rather important limitations and options for improvement. These have enabled us to refine and modify the final design and improve the main study in critical areas such as measures to limit contamination, inclusion criteria and outcome measures.
The authors would like to thank all participating patients and all general practice investigators and their teams (Drs Bauer, Bolender, Braun, Dörr, Draheim, Endruweit, Fink, Freise, Gerlach-Lüdeke, Göllner, Heiskel, Jablonski, Neuschild, Roser, Rothkegel, Sanner Schiek-Kunz, Sunnus, Thürmer, Vetter, Weismüller) and Petra Thuermann for conducting medication reviews during the MAI reliability study. The authors are grateful to our dedicated research team Zeycan Albay, Anja Paesel, Mareike Leifermann, Anne Namyst and to Gisela Kassner. The authors also thank our practice advisory board Joachim Fessler, Joachim Seffrin, Karola Mergenthal and Vera Müller. This study was only possible thanks to their extraordinary engagement. Furthermore, the authors would like to acknowledge the tremendous work of Kristina Zint, Jens Kaltschmidt and Michael Metzner in developing and programming the study version of the CDSS. The authors thank Sven Schulz and Jochen Gensichen for the prepiloting of the MediMoL and data collection instruments and Cornelia Mahler for the provision of the German versions of MARS and BMQ. The authors would also like to thank Professor Paul Glasziou and the participants of the journal club at CREBP, Bond University, QLD, Australia for inspiring discussions on the MAI and particularly Elaine Beller for her support in the sample size calculation of the MAI reliability study. Further, the authors would like to acknowledge the work of Phillip Elliott in translating the MediMoL and quotations from interviews, and proofreading the manuscript.
Contributors CM drafted the manuscript, coordinated the study and contributed to the conception, design, data collection and data analyses. JR contributed to the conception, design and data analyses. WEH contributed to the conception and design and provided the study version of CDSS. SH contributed to the conception and design and conducted the MAI ratings. BF and LU contributed to the design, data collection and analyses. CG, AE and MB contributed to the conception and design and supported the recruitment of practices. RP, MvdA, AK, JVM and FMG provided advice on the conception, design and coordination of the study. All authors critically revised and agreed on the final version of the manuscript.
Funding Funding has been provided by the German Federal Ministry of Education and Research, BMBF, grant number 01GK0702.
Competing interests CM, LU, BF, CMV, AE, CG, JAK, JR, RP, SH and MB have nothing to disclose. WEH is a member of the scientific advisory board and a shareholder of Dosing GmbH, the company distributing the clinical decision support software used in this study. His wife is an employee of Dosing GmbH.
Ethics approval Institutional Review Board at University Hospital, Goethe University, number 54/09, 24/03/2009.
Provenance and peer review Not commissioned; externally peer reviewed.
Data sharing statement No additional data are available.
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