- Research article
- Open Access
Modelling seizure rates rather than time to an event within clinical trials of antiepileptic drugs
BMC Medical Research Methodology volume 20, Article number: 84 (2020)
Predictive models within epilepsy are frequently developed via Cox’s proportional hazards models. These models estimate risk of a specified event such as 12-month remission. They are relatively simple to produce, have familiar output, and are useful to answer questions about short-term prognosis. However, the Cox model only considers time to first event rather than all seizures after starting treatment for example. This makes assessing change in seizure rates over time difficult. Variants to the Cox model exist enabling recurrent events to be modelled. One such variant is the Prentice, Williams and Peterson – Total Time (PWP-TT) model. An alternative is the negative binomial model for event counts. This study aims to demonstrate the differences between the three approaches, and to consider the benefits of the PWP-TT approach for assessing change in seizure rates over time.
Time to 12-month remission and time to first seizure after randomisation were modelled using the Cox model. Risk of seizure recurrence was modelled using the PWP-TT model, including all seizures across the whole follow-up period. Seizure counts were modelled using negative binomial regression. Differences between the approaches were demonstrated using participants recruited to the UK-based multi-centre Standard versus New Antiepileptic Drug (SANAD) study.
Results from the PWP-TT model were similar to those from the conventional Cox and negative binomial models. In general, the direction of effect was consistent although the variables included in the models and the significance of the predictors varied. The confidence intervals obtained via the PWP-TT model tended to be narrower due to the increase in statistical power of the model.
The Cox model is useful for determining the initial response to treatment and potentially informing when the next intervention may be required. The negative binomial model is useful for modelling event counts. The PWP-TT model extends the Cox model to all included events. This is useful in determining the longer-term effects of treatment policy. Such a model should be considered when designing future clinical trials in medical conditions typified by recurrent events to improve efficiency and statistical power as well as providing evidence regarding changes in event rates over time.
Epilepsy is defined as the tendency to have recurrent unprovoked seizures, and is one of the most prevalent chronic neurological conditions affecting approximately 70 million people worldwide . In clinical practice a key aim of treatment is to achieve freedom from seizures with minimal adverse effects from antiepileptic drugs.
Standard internationally recognised outcomes in epilepsy include time to 12-month remission and time to treatment failure , and are most frequently modelled via Cox proportional hazards models. These models estimate risk of a specified event, are relatively simple to fit and have easily interpretable output. They are particularly useful to assess clinically relevant outcomes such as time to first seizure after commencement of treatment, as that is the time at which a change in treatment may happen.
The Cox model has notable disadvantages. In particular, it models time to one particular event after time zero such as time to 12-month remission from seizures, rather than modelling each seizure that occurs after randomisation in a clinical trial. Indeed, estimates suggest that 60 to 70% of people with epilepsy will achieve a remission from seizures . However, up to 37% of people who achieve remission may proceed to have at least one further seizure whilst on antiepileptic drugs . Considering time to first event only could limit the assessment of treatment policy and the ability to provide patients with an up-to-date prognosis following seizure occurrence.
When the event of interest, such as a seizure in epilepsy, can occur more than once in a participant, the events are termed recurrent events. Several approaches have been proposed to account for intra-subject correlation that arises from multiple events in survival analysis. These include variants to the Cox model [5, 6]. The most appropriate of these, based on the model assumptions and the clinical reality that seizures cluster and thus may not occur independently , is the Prentice, Williams and Peterson – Total Time (PWP-TT) model . The PWP-TT model considers cumulative time since randomisation per event. An alternative is modelling event counts which can be done using negative binomial regression modelling.
Results from these three models have different interpretations. Cox models describe the risk of a specified event i.e. the first seizure after randomisation, or the first period of 12-month remission from seizures following randomisation. From a clinical perspective this is helpful to estimate when the next event of interest might happen from time zero. The PWP-TT and negative binomial models describe the rate of the event (i.e. number of events over a fixed time period) and can be used to assess the impact of longer-term policy on seizure frequency, as well as remission, within epilepsy.
The aim of this paper is to demonstrate the differences between the three approaches, and to highlight the benefits of the PWP-TT approach for assessing change in seizure rates over time. Included participants were those recruited to the UK-based multi-centre Standard versus New Antiepileptic Drug (SANAD) study.
Patients and procedures
Full details of the SANAD study are available in the original trial publications [9, 10]. Briefly, participants were eligible for randomisation into the SANAD study if they had a history of two or more clinically definite unprovoked epileptic seizures in the previous year. They were recruited to arm A if the recruiting clinician regarded carbamazepine the better standard treatment option than valproate, and arm B if the recruiting clinician regarded valproate the better standard treatment option than carbamazepine. In arm A, between 1st December 1999 and 1st June 2001, participants were allocated in a ratio of 1:1:1:1 to receive carbamazepine, gabapentin, lamotrigine or topiramate. From 1st June 2001 to 31st August 2004, an oxcarbazepine group was added to the trial and participants were randomly allocated in a ratio of 1:1:1:1:1 to receive carbamazepine, gabapentin, lamotrigine, oxcarbazepine, or topiramate. Within arm B, participants were allocated randomly in a 1:1:1 ratio to valproate, lamotrigine or topiramate between 12th January 1999 and 31st August 2004.
The primary outcomes across the SANAD study were time to treatment failure and time to 12 months of remission from seizures. Secondary outcomes included time to first post-randomisation seizure.
Cox’s proportional hazards regression model was used to model time to first seizure post randomisation and time to 12-month remission as these are frequently reported outcomes within the clinical literature. Full details of the methodology used to develop the prognostic model for time to 12-month remission for participants in SANAD have been reported previously [11, 12]. Identical methods were used for time to first seizure from randomisation. In brief, a pool of potential prognostic factors was established and a multivariable Cox model was derived by backwards selection according to Akaike’s Information Criterion . Continuous variables were investigated using fractional polynomial transformations [14,15,16,17], and presented as post-hoc defined categorical variables with categories chosen based on knot positions for a spline model fit to the variable . Similar methodology was used to model event counts, via the negative binomial model.
The PWP-TT model was used to estimate the rate of recurrent seizures based on data collected over the full study. It is a multiple time-to-event approach to modelling the data and accounts for missing data via censoring . It assumes that subjects cannot be at risk for say a fourth seizure until they have a third seizure, which is a valid clinical assumption within epilepsy. The PWP-TT model enables inclusion of all post-randomisation seizures, not just the first for example. As for the Cox models, variables from the pool of potential prognostic factors were included in a multivariable model via backwards selection according to Akaike’s Information Criterion,  and continuous covariates were assessed for best fit.
The list of possible prognostic factors for inclusion in the models was developed based on clinical consensus and previous related publications [20, 21]: gender, febrile seizure history, first degree relative with epilepsy, treatment history (antiepileptic drug treatment prior to randomisation), age at randomisation, annual rate of tonic-clonic seizures prior to randomisation (total number of tonic-clonic seizures prior to randomisation divided by time from first seizure to randomisation), neurological insult (learning disabilities or a neurological deficit), electroencephalogram (EEG) result, and seizure type. EEG result was classified as normal, not done, non-specific abnormality, or epileptiform abnormality (focal or generalised spikes, or spike and slow wave activity). Additionally, focal epilepsy site of onset and CT or MRI scan result were also included in the pool of possible factors for arm A of the study.
Treatment was forced into each model as all participants were treated at randomisation. As only 44 participants were classified as having generalised epilepsy in arm A, and only 54 participants were classified as having focal epilepsy in arm B these participants were excluded from this analysis. Therefore arm A included 1491 participants with focal epilepsy and 157 with unclassified epilepsy, and arm B included 464 participants with generalised epilepsy and 184 participants with unclassified epilepsy. The two arms were modelled separately.
In the development of prognostic models for time to 12-month remission and time to treatment failure previously [11, 22], stratification was used to account for the late addition of oxcarbazepine to the arm A of the study. However, this was found to have little effect on the results  and so the stratification term was dropped to ensure that all drugs could be included in the PWP-TT and negative binomial models.
The initial comparison between models used the data from arm A as it was the largest dataset. However, arm B data was also considered to determine the generalisability of the results. A number of sensitivity analyses were also considered, again to determine the generalisability of the results. In particular, in SANAD clinicians were free to prescribe any treatment they deemed appropriate after withdrawal of the randomised drug. Therefore, the dataset includes many possible drug combinations which adds complexity to the statistical model. Therefore two approaches were taken; include everyone, and censor people at the time when they come off their randomised drug. Additionally, sensitivity analyses considered recurrent tonic-clonic seizures only (arm A and B) and recurrent tonic-clonic and complex partial seizures only (arm A).
Outcome data were available for 1648 participants in arm A and 637 in arm B. 443 arm A participants had zero seizures during follow-up and of these, 380 (86%) people were classified as having focal epilepsy. 200 arm B participants had zero seizures during follow-up and of these, 123 (62%) people were classified as having generalised epilepsy. The annual rate of seizures, per seizure type, for participants with seizures post-randomisation in arms A and B can be seen in Fig. 1. Arm A participants had a median rate of about 10 seizures per year across the three seizure types. Arm B groups were more variable, but generally had higher seizure frequency.
Arm A – focal epilepsy
Table 1 summarises the effect of treatment on outcome according to each of the four models - two Cox, negative binomial and the PWP-TT. The difference in interpretation between the Cox and PWP-TT models can be illustrated graphically as in Fig. 2. This figure was generated based on the median time to first seizure per treatment group in the case of the Cox model (shown in black), and randomly generated times from the uniform distribution based on the median number of predicted seizures per treatment group based on the PWP-TT model (shown in red). Although carbamazepine, oxcarbazepine and topiramate have the longest times to first seizure, in the longer term oxcarbazepine shows a lower number of seizures than both carbamazepine and topiramate. As a rate of zero indicates remission, lower average seizures rates imply more people achieving remission.
According to the Cox models (Table 1), risk of first seizure and chance of not achieving 12-month remission are significantly higher on gabapentin than carbamazepine – chance of not achieving 12-month remission is equivalent to 1 divided by the chance of the event. A short time to first seizure implies a higher chance of not achieving 12 month remission, which is reflected in the two Cox models estimating gabapentin and lamotrigine to be less effective than carbamazepine. Median time to first seizure on lamotrigine is 37 days shorter than carbamazepine and median time to remission is 120 days shorter on carbamazepine than on lamotrigine. These results are broadly in line with the negative binomial model which shows rate of seizures is significantly higher on gabapentin than carbamazepine and significantly lower on oxcarbazepine than carbamazepine.
According to the PWP-TT model (Table 1), people on topiramate have a 6% higher rate of recurrent seizures than those on carbamazepine. The direction of the effect is generally opposite to that for the Cox models and none of the results are significant. Therefore, taking all four models into consideration, gabapentin and lamotrigine appear worse at delaying a first seizure than carbamazepine. In the longer term there is less difference between the treatment policies because if the first treatment does not work, it will be changed, and if necessary changed again, aiming for seizure control. The PWP-TT model better captures the longer term consequence of this treatment policy. The size of effect is closer to zero with narrower confidence intervals for the PWP-TT model than the results seen with the Cox and negative binomial models. This is because the statistical power is maximised in the PWP-TT model .
The multivariable PWP-TT model included all potential covariates except for age; the Cox and negative binomial models included fewer covariates as shown in Table 2. As the multivariable PWP-TT model is more powerful for rate of recurrent seizures, more potential covariates with narrower confidence intervals are included than with either Cox model. The Cox models did not include febrile seizure history, first degree relative with epilepsy and EEG result. The negative binomial model did include EEG result but additionally neurological insult, focal site of onset, and annual rate of seizures prior to randomisation were excluded from the model. No drug has significantly higher seizure rates than carbamazepine, but gabapentin was significant in both Cox models and gabapentin was significant in the negative binomial model.
The PWP-TT model estimated a 10% lower seizure recurrence rate among people with simple or complex partial seizures only compared to those with simple or complex partial seizures and generalised tonic-clonic seizures. People with uncertain seizure types had long-term seizure rates almost twice that of people with simple or complex partial seizures only. The results also suggest that people with a low rate of seizures prior to randomisation have a higher rate of recurrent seizures than those with higher rates prior to randomisation.
The direction of the effect for most statistically significant variables was the same across models, with the PWP-TT coefficients shrunk towards one. Differences in direction of estimated effect are likely due to the different variables include in the multivariable model and the resulting effect on the interactions between these variables.
A forest plot comparing median seizure counts (in blue) predicted from the PWP-TT model according to combinations of patient characteristics can be seen in Fig. 3. The associated observed seizure counts are also included for comparison (in red). Gender is the most influential factor with women having higher predicted and observed seizure counts within 2 years of randomisation than men, and thus lowest chance of remission.
Arm B – generalised epilepsy
For comparison, identical analyses were considered using the data from arm B. Table 3 summarises the effect of treatment on outcome according to each of the four models.
The difference in interpretation between the Cox and PWP-TT models is again illustrated graphically, in Fig. 4. Although valproate has a slightly longer median time to remission than topiramate, in the longer term both valproate and topiramate lead to a lower number of seizures than lamotrigine. According to the Cox models, risk of first seizure and chance of not achieving 12-month remission (1/chance of remission) are significantly higher on lamotrigine than valproate. A short time to first seizure implies a higher chance of not achieving 12 month remission, which is reflected in the two Cox models estimating lamotrigine to be less effective than valproate. Rate of seizures are also higher on lamotrigine and topiramate than valproate according to the negative binomial model.
According to the PWP-TT model, people on lamotrigine have a 12% higher rate of recurrent seizures than those on valproate on average, and 13% higher in participants on topiramate than on valproate. The direction of the effect is in agreement with that from the Cox models but only the result for topiramate is significant. Therefore, taking all four models into consideration, valproate is much better at delaying a first seizure than lamotrigine and topiramate, but in the longer term there is less difference in the effect of treatment policies on seizure rate and remission. Again, the size of the effect is closer to zero with narrower confidence intervals for the PWP-TT than the results seen with the Cox and negative binomial models as the power is maximised.
As the multivariable PWP-TT model is more powerful for rate of recurrent seizures, more potential covariates with narrower confidence intervals are included than with either Cox model (Table 4). The Cox models did not include febrile seizure history or EEG result. The negative binomial included febrile seizure history but additionally excluded gender and annual rate of seizures prior to randomisation. Topiramate had significantly higher seizure rates than valproate, but was not significant in the Cox or negative binomial models.
The The PWP-TT model estimated estimated a 28% lower rate of recurrent seizures among people with a history of febrile seizures than those who did not have such a history, and participants with seizures after a period of remission had a lower rate than treatment naïve participants. People with a neurological insult and those on lamotrigine or topiramate had higher rates of recurrent seizures than those on valproate. Older participants (over 50) had seizure recurrence rates 13% lower than those aged less than eight.
The PWP-TT results imply that valproate has a longer expected time to first seizure and shorter time to remission. The direction of the effect for most statistically significant variables was the same across models with the PWP-TT coefficients shrunk towards one. Differences in direction of estimated effect are again likely due to the different variables included in the multivariable model and the resulting effect on the interactions between these variables.
A forest plot comparing median seizure counts (in blue) predicted from the PWP-TT model according to combinations of patient characteristics can be seen in Fig. 5. The associated observed seizure counts are also included for comparison (in red). Age is the most influential factor with the youngest people having the highest predicted seizure count within 2 years of randomisation, and thus lowest chance of remission.
Sensitivity analyses – PWP-TT model
Arm A – focal epilepsy
Sensitivity analyses of the PWP-TT model with censoring at withdrawal of randomised drug, and based on specific recurrent seizure types for patients in arm A can be seen in Table 5. The results for recurrent tonic-clonic seizures only, and recurrent tonic-clonic and complex partial seizures only are the same suggesting that the predicted rate of these seizures is similar. Censoring at withdrawal of randomised drug has little effect on the results, although the direction of effect for gabapentin changes and the results for gabapentin and topiramate become significant when the model is unadjusted for any other variables.
The results for the multivariable PWP-TT models according to each sensitivity analysis can be seen in Table 6. In general fewer variables were included in the multivariable models than seen in the original PWP-TT model. The direction of effect is generally consistent with the original results.
Arm B – generalised epilepsy
Sensitivity analyses of the PWP-TT model with censoring at withdrawal of randomised drug, and based on specific recurrent seizure types for patients in arm B can be seen in Table 7. The varying conditions had little effect on the results which maintain their significance and direction. The results for the multivariable PWP-TT models according to each sensitivity analysis can be seen in Table 8. In general fewer variables were included in the models than seen originally. The direction of effect is generally consistent with the original results.
The PWP-TT model for focal epilepsy suggests that participants with a relative with epilepsy have a lower rate of recurrent seizures than people without such a relative, and that people with an abnormal CT/MRI scan results have a higher rate of recurrent seizures than those with a normal scan result. People with frontal lobe, other, or unclassified site of onset have a lower rate of recurrent seizures than people with temporal lobe site of onset. Additionally, people with simple or complex seizures with generalised tonic-clonic seizures, and people with uncertain seizure type have a higher rate of recurrent seizures than people with simple or complex partial seizures. Also, people with a higher rate of seizures before randomisation have a lower rate of recurrent seizures than those with a lower rate of seizures before randomisation. This final result is contrary to expectation but is due to an interaction with febrile seizure history (p-value: 0.03): the few people who had febrile seizures had higher pre-randomisation rates. This interaction term is not included in the model, as it vastly increases the complexity of the model interpretation.
The PWP-TT model for generalised epilepsy suggests that participants restarting treatment following seizures after remission have a lower rate of recurrent seizures than treatment naïve participants, that young participants (less than or equal to seven) have a lower rate of recurrent seizures than those aged eight or above, and that people with neurological insult have a higher rate of recurrent seizures than those without such an insult. Additionally, participants with febrile seizure history have a lower rate of recurrent seizure those who did not have such a history. Clinical intuition would suggest that participants with a febrile history seizure have a poorer clinical outcome. However, a history of febrile seizures is more often associated with focal epilepsy rather than generalised and unclassified as considered here [11, 22]. This, combined with the fact that only 8% of participants under consideration here had a history of febrile seizures, potentially explains this spurious finding.
The results of the Cox models have been discussed previously [11, 22]. While it is not appropriate to directly compare the results from the PWP-CTT model with those for conventional Cox models, we found that the results were fairly similar. Similarly the results of the negative binomial models. In general the direction of effect was consistent even if the significance of the covariate was not. Observed differences are likely to result from the number of variables included in the model, the underlying baseline hazard function, and the statistical power of the models. In particular, traditional Cox models consider a specific event with a fixed underlying intensity function while the PWP-TT model enables the underlying intensity function to vary from event to event .
The PWP-TT model accounts for all events along a patients’ journey and models time between each event. It also has improved statistical power over the Cox and negative binomial models. The PWP-TT model additionally estimates risk of future recurrent events rather than just time to a specified event. However, the data set-up is quite complex and the size of the dataset can be very large, especially for clinical conditions with many recurrent events such as seizures in epilepsy. Additionally the addition precision of the PWP-TT model is mirrored by a slight reduction in the ease of interpretation of the output.
A limitation of this analysis is the way the seizure data were collected within SANAD. Specifically, people were asked to report number of seizures since their previous appointment together with the date of the most recent seizure and first seizure since the last appointment. Therefore, dates of specific seizures were not collected. There is some evidence to suggest that seizures beget seizures . However, we have not been able to investigate this further, specifically regarding treatment effect between the PWP-TT and negative binomial models, due to the limitations of this, and most routinely collected data within epilepsy trials.
Few published analyses of clinical data have utilised the PWP-TT model. Those that have include an analysis of diarrhoeal episodes in children , a population-based study of repetitive traumatic brain injury among persons with traumatic brain injury , recurrent malaria episodes , and childhood infectious diseases . Such a model should be considered when designing future clinical trials in medical conditions typified by recurrent events, to ensure improve efficiency and statistical power as well as providing evidence regarding changes in event rates over time.
Cox’s proportional hazard model is frequently used within the clinical literature to model time to a specified event. As demonstrated in this manuscript, this is useful for determining the initial response to treatment and potentially informing when the next intervention may be required. A variant on the Cox model, the PWP-TT, extends the Cox model to consider all events, not just the first. An alternative is the negative binomial model which considers event counts. We have shown the PWP-TT model to be useful to determine the longer-term effects of treatment policy. The PWP-TT model is therefore useful to increase understanding of chronic diseases.
Further work is now required to validate these epilepsy models in alternative data. The most relevant independent data will be the results from the SANAD II study which are not due to be released until the end of 2019 at the earliest.
Availability of data and materials
The datasets analysed during the current study are not publicly available as they contain information that could comprise the privacy of participants but are available from Professor Marson (A.G.Marson@liverpool.ac.uk) on reasonable request.
Magnetic resonance imaging
Prentice, Williams and Peterson – Total Time
Standard versus New Antiepileptic Drug
Ngugi AK, Bottomley C, Kleinschmidt I, Sander JW, Newton CR. Estimation of the burden of active and life-time epilepsy: a meta-analytic approach. Epilepsia. 2010;51(5):883–90.
Anon. Considerations on designing clinical trials to evaluate the place of new antiepileptic drugs in the treatment of newly diagnosed and chronic patients with epilepsy. Epilepsia. 1998;39(7):799–803.
Cockerell OC, Johnson AL, Sander JWAS, Hart YM, Shorvon SD. Remission of epilepsy - results from the National General-Practice Study of epilepsy. Lancet. 1995;346(8968):140–4.
Pellock JM, Dodson WE, Bourgeois BF. Pediatric epilepsy: diagnosis and therapy :third edition: springer publishing company; 2008.
Therneau TM, Hamilton SA. rhDNase as an example of recurrent event analysis. Stat Med. 1997;16(18):2029–47.
Kelly PJ, Lim LLY. Survival analysis for recurrent event data: an application to childhood infectious diseases. Stat Med. 2000;19(1):13–33.
Berg AT, Shinnar S. Do seizures beget seizures? An assessment of the clinical evidence in humans. J Clin Neurophysiol. 1997;14(2):102–10.
Prentice RL, Williams BJ, Peterson AV. On the regression analysis of multivariate failure time data. Biometrika. 1981;68(2):373–9.
Marson AG, Al-Kharusi AM, Alwaidh M, Appleton R, Baker GA, Chadwick DW, et al. The SANAD study of effectiveness of valproate, lamotrigine, or topiramate for generalised and unclassifiable epilepsy: an unblinded randomised controlled trial. Lancet. 2007;369(9566):1016–26.
Marson AG, Al-Kharusi AM, Alwaidh M, Appleton R, Baker GA, Chadwick DW, et al. The SANAD study of effectiveness of carbamazepine, gabapentin, lamotrigine, oxcarbazepine, or topiramate for treatment of partial epilepsy: an unblinded randomised controlled trial. Lancet. 2007;369(9566):1000–15.
Bonnett LJ, Tudur Smith C, Smith D, Williamson PR, Chadwick D, Marson AG. Time to 12-month remission and treatment failure for generalised and unclassified epilepsy. J Neurol Neurosurg Psychiatry. 2013;85(6):603–10.
Marson AG, Appleton R, Baker GA, Chadwick DW, Doughty J, Eaton B, et al A randomised controlled trial examining the longer-term outcomes of standard versus new antiepileptic drugs. The SANAD trial. Health Technol Assess. 2007;11(37):iii-iv, ix-x, 1–134.
Akaike H. A new look at the statistical model identification. Automatic Control IEEE Transactions On. 1974;19(6):716–23.
Royston P, Altman DG. Regression using fractional polynomials of continuous covariates - parsimonious parametric modeling. Appl Stat J Royal Stat Soc Series C. 1994;43(3):429–67.
Royston P, Ambler G, Sauerbrei W. The use of fractional polynomials to model continuous risk variables in epidemiology. Int J Epidemiol. 1999;28(5):964–74.
Royston P, Sauerbrei W. Multivariable model-building - a pragmatic approach to regression analysis based on fractional polynomials for modelling continuous variables: Wiley; 2008.
Royston P, Sauerbrei W. Building multivariable regression models with continuous covariates in clinical epidemiology--with an emphasis on fractional polynomials. Methods Inf Med. 2005;44(4):561–71.
Stone CJ. Additive regression and other nonparametric models. Ann Stat. 1985;13(2):689–705.
Prentice RL, Farewell VT. Relative risk and odds ratio regression. Annu Rev Public Health. 1986;7:35–58.
Kim LG, Johnson TL, Marson AG, Chadwick DW. Prediction of risk of seizure recurrence after a single seizure and early epilepsy: further results from the MESS trial. Lancet Neurol. 2006;5(4):317–22.
MacDonald BK, Johnson AL, Goodridge DM, Cockerell OC, Sander JWAS, Shorvon SD. Factors predicting prognosis of epilepsy after presentation with seizures. Ann Neurol. 2000;48(6):833–41.
Bonnett L, Smith CT, Smith D, Williamson P, Chadwick D, Marson AG. Prognostic factors for time to treatment failure and time to 12 months of remission for patients with focal epilepsy: post-hoc, subgroup analyses of data from the SANAD trial. Lancet Neurol. 2012;11(4):331–40.
Rizopoulos D Joint models for longitudinal and time-to-event data: with applications in R: chapman and hall/CRC; 2012.
Schmidt W-P, Cairncross S, Barreto ML, Clasen T, Genser B. Recent diarrhoeal illness and risk of lower respiratory infections in children under the age of 5 years. Int J Epidemiol. 2009;38(3):766–72.
Saunders LL, Selassie AW, Hill EG, Nicholas JS, Horner MD, Corrigan JD, et al. A population-based study of repetitive traumatic brain injury among persons with traumatic brain injury. Brain Inj. 2009;23(11):866–72.
Sagara I, Giorgi R, Doumbo OK, Piarroux R, Gaudart J. Modelling recurrent events: comparison of statistical models with continuous and discontinuous risk intervals on recurrent malaria episodes data. Malaria Journal. 2014;13:293-.
Laura Bonnett is funded by a National Institute for Health Research (NIHR) Post-Doctoral Fellowship (PDF-2015-08-044) for this research project. This publication presents independent research funded by the NIHR. The views expressed are those of the author(s) and not necessarily those of the NHS, the NIHR or the Department of Health and Social Care.
Professor Tony Marson was part-funded by the National Institute for Health Research (NIHR) Applied Research Collaboration North West Coast (ARC NWC). The views expressed are those of the authors and not necessarily those of the NIHR or the Department of Health and Social Care.
Ethics approval and consent to participate
SANAD received appropriate multicentre and local ethics and research committee approvals from the National Multi-Centre Research Ethics Committee North West (MREC 98/8/62), and was managed according to the Medical Research Council’s Good Clinical Practice Guidelines. Patients gave informed written consent to inclusion and to long-term follow-up. In the case of children (< 16 years), consent was obtained from the parent or guardian.
SANAD is registered as an International Standard Randomised Controlled Trial, number ISRCTN38354748.
Consent for publication
The authors declare that they have no competing interests.
Springer Nature remains neutral with regard to jurisdictional claims in published maps and institutional affiliations.
About this article
Cite this article
Bonnett, L.J., Hutton, J.L. & Marson, A.G. Modelling seizure rates rather than time to an event within clinical trials of antiepileptic drugs. BMC Med Res Methodol 20, 84 (2020). https://doi.org/10.1186/s12874-020-00965-5
- Cox model
- Negative binomial