 Research article
 Open access
 Published:
Transferability of health cost evaluation across locations in oncology: cluster and principal component analysis as an explorative tool
BMC Health Services Research volume 14, Article number: 537 (2014)
Abstract
Background
The transferability of economic evaluation in health care is of increasing interest in today’s globalized environment. Here, we propose a methodology for assessing the variability of data elements in cost evaluations in oncology. This method was tested in the context of the European Network of Excellence “Connective Tissues Cancers Network”.
Methods
Using a database that was previously aimed at exploring sarcoma management practices in RhôneAlpes (France) and Veneto (Italy), we developed a model to assess the transferability of health cost evaluation across different locations. A nested data structure with 60 final factors of variability (e.g., unit cost of chest radiograph) within 16 variability areas (e.g., unit cost of imaging) within 12 objects (e.g., diagnoses) was produced in Italy and France, separately. Distances between objects were measured by Euclidean distance, Mahalanobis distance, and cityblock metric. A hierarchical structure using cluster analysis (CA) was constructed. The objects were also represented by their projections and area of variability through correlation studies using principal component analysis (PCA). Finally, a hierarchical clustering based on principal components was performed.
Results
CA suggested four clusters of objects: chemotherapy in France; followup with relapse in Italy; diagnosis, surgery, radiotherapy, chemotherapy, and followup without relapse in Italy; and diagnosis, surgery, and followup with or without relapse in France. The variability between clusters was high, suggesting a lower transferability of results. Also, PCA showed a high variability (i.e. lower transferability) for diagnosis between both countries with regard to the quantities and unit costs of biopsies.
Conclusion
CA and PCA were found to be useful for assessing the variability of cost evaluations across countries. In future studies, regression methods could be applied after these methods to elucidate the determinants of the differences found in these analyses.
Background
Economic evaluations have become an integral part of healthcare decisionmaking worldwide; however, cost assessments are time consuming, expensive, and not systematically reproducible. The value of these studies, according to Nixon, is determined by the methods used and transparency in reporting [1]. Although the number of economic evaluations of pharmacoeconomic guidelines has increased, the use of economic evaluations in other jurisdictions usually requires the implementation of methodological adaptations for the specific environment under investigation [2],[3].
Sculpher et al. suggested that the generalizability of economic evaluations is based on the extent to which results from a study of a particular patient population and/or specific context can be transposed to another population and/or a different context [4]. Alternatively, transferability represents the ability to substitute local data with data from other environments, allowing the analysis to be easily applied to other settings or countries [1]. Generally, the data used in economic evaluations include pricing (unit costs of resources used and quantities) and clinical practices (characteristics of disease and corresponding procedures of diagnosis, treatment, and followup).
After the pioneering work of Drummond [5], many authors have employed a qualitative approach, which is based on systems, tools, checklists, and flow charts, in order to assess or guide transferability practices during economic evaluation. This topic has been recently reviewed by Goeree [6].
Quantitative methods, mainly based on regression modeling, have been largely used to explain variability in costs and/or costeffectiveness by location [7][15]. More specifically, multilevel regression models were employed to analyze data that fall naturally into hierarchical structures, consisting of multiple macro units (countries) and multiple micro units (centers) within each macro unit [4]. We aim to achieve an overall picture of things, which could make it possible to focus on the main problems and identify hypotheses using cluster analysis (CA) and principal component analysis (PCA). CA and PCA are examples of how distances and the assumption of correlations among numerous quantitative variables can be used to display whether the phenomena are near or far in a simple plot. Regression methods could be applied after such explorative analyses to recognize the determinants of the differences found.
To our knowledge, only one abstract using CA to explore the transferability of cost assessment among countries has been published [16], while none have utilized PCA. In the present study we have used both methods, CA and PCA, to assess the variability of health care costs in sarcoma management in two European regions, RhôneAlpes (France) and Veneto (Italy). The rarity of these tumors and the large variability in their clinical and histopathological presentation makes the standardization of therapeutic sequences difficult, making this research particularly important with respect to transferability of its economic evaluation [17].
The objective of the research was then to ascertain the contributions of various stages of cancer care, more specifically their unit costs and resource use to between country differences.
Methods
Our initial cohort consisted of 327 sarcoma patients who were ≥15 yearsold (254 in Veneto, Italy and 73 in RhôneAlpes, France). All patients had histological confirmation of primary malignant sarcoma, with or without distal metastases at initial diagnosis. All patients from RhôneAlpes (n = 73) had been diagnosed between March 2005 and February 2006 and were recruited from two sites (the University Hospital of Lyon and the Léon Bérard Cancer Centre). The patients from Veneto (n = 161) were diagnosed between January 2007 and December 2007 and recruited at one of the 22 public hospitals in the region. Absence of patient consent (n = 55), care undertaken outside the participating regions or in private hospitals (n = 23), and missing records (n = 30) reduced the number of patients included in the study to 219, 58 from RhôneAlpes and 161 from Veneto [17]. These patients were followed retrospectively using prospectively implemented databases for three years after their initial sarcoma diagnosis or until death. In addition, patients were managed in accordance with the ethical principles for medical research involving human subjects described in the Declaration of Helsinki. The cost evaluation of the 219 sarcoma patients began in 2009. For each patient, quantities of resources used (number of days in hospital, cycles and doses of chemotherapy, number of transfusions, radiotherapy sessions, imaging procedures, biopsies, surgical process and consultations) were collected for each sequences of management (i.e. initial diagnosis, initial surgery, chemotherapy, radiotherapy, followup with relapsed patients, and followup with healthy patients). Costs were assessed from the hospital’s perspective from the time of diagnosis to the end of followup (or death), designating the country (France or Italy) and the sequence of management. Average unit costs were assessed for France and Italy respectively and applied in respect to the patient management country of origin. All costs were expressed in 2009 euro. 4% discounting per year was applied according to the French Health Authority’s recommendation to both countries [18]. The study received approval in France from the National Ethics Committee (N°904073) and the National Committee for Protection of Personal Data (N°051102), and from the Local Sanitary Agency of the Veneto Region and the Ethics Committee of the Azienda Ospedaliera di Padova (N°156/06/CE) in Italy. Data were collected within the context of the European network of excellence “Connective Tissues Cancers Network” (CONTICANET, FP6 018806), which is funded by the European Commission. The full protocol of the project has been previously published [19],[20].
Definition
Welte and Sculpher suggested that, in order to clearly structure the transferability assessment, it is necessary to systematically identify the factors that impact the variability (final factors) and to gather them into homogeneous categories (areas of variability) [21],[4]. Accordantly to model the problem of assessing transferability of health cost evaluation across locations we identified 60 final factors of variability (e.g. unit cost of chest radiograph). In addition to fit better our data regarding entire management process of a sarcoma disease we applied a nested structure within 16 variability areas (e.g. unit cost of imaging) and within 12 objects (e.g. diagnoses) in Italy and France, independently.
Identification of potential and final factors of variability
A factor is a potential source of variability in the relative prices and quantities (i.e. unit cost, number of surgical biopsies, radiotherapy sessions, etc.). They were identified from the literature [1],[4][6],[22][24]. Only those factors that varied from one to another country were included in the analysis (final factors), i.e. factors that do not vary with geography were not included.
Area of variability
Each area of variability included a set of final factors. The complete list of final factors within these areas is reported in Table 1. An example of an area is the “area quantity of imaging”, which included five final factors: “chest radiograph”, “colonoscopy”, “computed tomography”, “ultrasound”, and “magnetic resonance imaging”. Since each final factor can vary according to “unit cost” and “number of resources used”, a total of 16 (8 × 2 = 16) areas of variability were generated (Table 1). For example, imaging was classified in Area 3 considering resources used and Area 11 considering costs.
Formally, the values of the n = 16 areas of variability for m = 12 objects give a matrix A _{(mxn)} with the general term α_{ ij } with α_{ ij } ≥0.
To overcome variability due to differences in monetary units and/or quantity of health resources used, all of the variables were standardized, passing from the matrix A _{(mxn)} = [α_{ ij }] to the matrix X _{(mxn)} = [x _{ ij }] where:
Object
Six phases of management (diagnosis, surgery, chemotherapy, radiotherapy, followup with relapsed patients, and followup with healthy patients) and two countries (Italy and France) were delineated. We therefore generated 12 objects (6 × 2 = 12), which included: diagnosis in France (object 1); diagnosis in Italy (object 2); surgery in France (object 3); surgery in Italy (object 4); chemotherapy in France (object 5); chemotherapy in Italy (object 6); radiotherapy in France (object 7); radiotherapy in Italy (object 8); followup without relapse in France (object 9); followup without relapse in Italy (object 10); followup with relapse in France (object 11); and followup with relapse in Italy (object 12).
Statistical analysis
An individual patient level dataset was completed accounting for resources consumed during the defined time period of the study, broken down into different phases of care (objects) and different areas (e.g. quantity of biopsies) per country and also accounting for the average unit cost of resource per country.
Cluster analysis
Cluster analysis involves assigning a set of objects into groups (called clusters) so that the objects in the same cluster are more similar to each other than to those in other clusters. Clustering required three steps in order to define the following parameters: distances, hierarchical structure, and optimal number of clusters [25].
First, the distances between all the pairs of objects can be evaluated using Euclidean distance, Mahalanobis distance, and cityblock metric [26]. Given an mbyn data matrix X, which is treated as m (1byn) row vectors x _{1},x _{2},...,x _{ m }, the various distances between the vector x _{ r } and x _{ s } are defined as follows:
(i) Euclidean distance: {d}_{rs}^{2}=\left({x}_{r}{x}_{s}\right)\phantom{\rule{0.5em}{0ex}}{\left({x}_{r}{x}_{s}\right)}^{}
Due to the preceding normalization this is in fact a `Standardized Euclidean distance’.

(ii)
Mahalanobis distance: {d}_{rs}^{2}={\left({x}_{r}{x}_{s}\right)}^{}{V}^{1}\left({x}_{r}{x}_{s}\right) where V is the sample covariance matrix.
(iii) City Block metric: {d}_{rs}={\displaystyle \sum _{j=1}^{n}\left{x}_{rj}{x}_{sj}\right}
However, when we used linkage procedures in a second stage, not all distances were relevant. Therefore, in order to make the best choice, we had to use the cophenetic correlation coefficient (see below).
Secondly, an iterative process (agglomerative hierarchical approach) was used to set a hierarchical structure. We put the distance information and link pairs of objects that were close together into binary clusters (made up of two objects). Then, these newly formed clusters were linked into larger clusters until all objects were linked together in a hierarchical tree. The hierarchical tree created by the linkage function was most easily understood when viewed graphically [27]. Therefore, we plotted this hierarchical information as a graph. The criteria used to compute distances between groups of objects were:

Single linkage: minimum distance criteria, using the smallest distance between objects in the two groups:
d\left(r,s\right)=min\left(\mathit{dist}\left({x}_{ri},{x}_{sj}\right)\right)\phantom{\rule{1.5em}{0ex}}i\in \left(1,...,{n}_{r}\right)\phantom{\rule{1em}{0ex}}j\in \left(1,...,{n}_{s}\right)\text{;}

Complete linkage: maximum distance criteria, using the largest distance between objects in the two groups:
d\left(r,s\right)=max\left(\mathit{dist}\left({x}_{ri},{x}_{sj}\right)\right)\phantom{\rule{1.5em}{0ex}}i\in \left(1,...,{n}_{r}\right)\phantom{\rule{1em}{0ex}}j\in \left(1,...,{n}_{s}\right)\text{;}

Average linkage: using the average distance between all pairs of objects in cluster r and cluster s:
d\left(r,s\right)=\frac{1}{{n}_{r}\times {n}_{s}}{\displaystyle \sum _{i=1}^{{n}_{r}}}{\displaystyle \sum _{j=1}^{{n}_{s}}}\mathit{dist}\left({x}_{ri},{x}_{sj}\right)\text{;}

Centroid linkage: using the distance between the centroids of the two groups:
d\left(r,s\right)=d\left({\stackrel{}{x}}_{r},{\stackrel{}{x}}_{s}\right)\phantom{\rule{1em}{0ex}}{\stackrel{}{x}}_{r}=\frac{1}{{n}_{r}}{\displaystyle \sum _{i=1}^{{n}_{r}}{x}_{ri}\phantom{\rule{1em}{0ex}}}{\stackrel{}{x}}_{s}=\frac{1}{{n}_{s}}{\displaystyle \sum _{j=1}^{{n}_{s}}{x}_{sj}}\phantom{\rule{1em}{0ex}}\text{;}

Ward linkage: using the incremental sum of squares (i.e. the increase in the total withingroup sum of squares as a result of joining groups r and s). It is given by:
d\left(r,s\right)=\frac{{n}_{r}\times {n}_{s}}{{n}_{r}+{n}_{s}}{d}^{2}\left(r,s\right)=\frac{{n}_{r}\times {n}_{s}}{{n}_{r}+{n}_{s}}d\left({\stackrel{}{x}}_{r},{\stackrel{}{x}}_{s}\right)\text{;}
Where d ^{2} (r,s) is the distance between cluster r and cluster s defined in the Centroid linkage. The withingroup sum of squares of a cluster is defined as the sum of the squares of the distance between all objects in the cluster and the centroid of the cluster. The cophenetic correlation coefficient, as defined below, was used to select the most appropriate combination (i.e. metrics, linkage procedure).
For the final step of the clustering process, the clustering solution was evaluated by computing the cophenetic correlation coefficient “c”; the closer the coefficient value was to 1, the better the clustering solution. If Y gives distances computed in the step 1, and Z signifies distances generated by a linkage method in the step 2, then the cophenetic correlation coefficient between Z and Y was defined as:
where:
Y _{ij} is the distance between objects i and j in Y.
Z _{ij} is the distance between objects i and j in Z.
y and z are the average of Y and Z, respectively.
The cophenetic correlation coefficient analyses are shown in Additional file 1. The best linkage method and the best distance are the pair (average; euclidean distance) with a cophenetic correlation coefficient equal to 0.83035.
A combination of good RSquare (RSQ) values was used to select the number of clusters to retain. More precisely, the optimum number of clusters to retain, which depends on homogeneity within cluster and/or heterogeneity between clusters, was assessed by RSQ, SemiPartial RSquared (SPRSQ), RootMeanSquare Standard Deviation (RMSSTD) and the pseudoF statistic (pF) [28],[29]. Methods and measures used for determining the optimal number of clusters are:

RSQ: RSQ measures the heterogeneity of the cluster solution formed at a given step. A large value represents that the clusters obtained at a given step are quite heterogeneous, whereas a small value signifies that the clusters formed at a given step are not very different from each other. It is therefore recommended to have a cluster solution with a high RSQ.

SPRSQ: The SPRSQ measures the loss of homogeneity due to the merging of two clusters to form a new cluster at a given step. If the value is small, then it suggests that the cluster solution obtained at a given step is formed by merging two very homogeneous clusters. On the other hand, large values of SPRSQ suggest that two heterogeneous clusters have been merged to form the new cluster. In general, a cluster solution with a low SPRSQ is preferred, as a high value for SPRSQ implies that two heterogeneous clusters are being merged.

RMSSTD: The RMSSTD measures the homogeneity of the cluster formed at any given step. It essentially measures the compactness or homogeneity of a cluster. Clusters in which consumers are very close to the centroid are compact clusters. The smaller the RMSSTD, the more homogeneous or compact the cluster formed is at a given step. A large RMSSTD value suggests that the cluster obtained at a given step is not homogeneous, and is probably formed by the merging of two heterogeneous clusters.

pF: The pF is intended to capture the tightness of clusters, and is a ratio of the mean sum of squares between groups to the mean sum of squares within groups. It makes it possible to compare the homogeneity of a partition in k classes with that of a partition in (k1) classes. A “strong” pF value at the level s will indicate a suitable partition in s classes correct. Peaks on the curve give the values of pF according to the number of classes.
As recommended in the literature, all measures were used as they relate to various properties of the clusters (see Figure 1).
Principal component analysis
To perform PCA, we began with the matrix X _{(m,n)}, where m corresponded to the 12 objects (i.e. observations or individuals in statistical terms) and n to the 16 areas of variability (i.e. the variables). Individuals and variables did not have symmetrical roles therefore we had a different representation in the factorial plane (or hyper plane), with a different interpretation [30],[31].
For individuals, we had m points that were located in the variable space R ^{n}. We then sought unit vectors u _{α} for defining a subspace of R ^{n} where in a projection of initial individualspoints was performed. Generally a projection is performed in the plane (R ^{2}). Vectors u _{α} were the eigenvectors of the matrix X ^{T} X, ranked in descending order of the corresponding eigenvalues. They were located on the factorial axes F _{α.} The coordinates of the m individual points on the factorial axis F _{α} were the m components of the vector ψ _{ α } = Xu _{ ψ }. The factor α _{ ψ } was a linear combination of the initial variables. Individuals were described by coordinates denoted ψ _{ α }(i). They were associated with the measurements denoted CTR_{α}(i) such that:
Individuals who made a strong contribution to the axis had a strong CTR_{α}(i) (Additional file 2). Moreover, if a variable x _{ j } was strongly correlated with, for example, ψ _{1} it meant that individuals with high positive (respectively negative) coordinates on axis 1 were characterized by a value of x _{ j } well above (respectively below) the average (since the origin of axes of interest is the center of gravity of the cloud).
A projection of the objects in the first two components was made, and here we have added a threedimensional graph because of the highest percentage of inertia of the first three components.
For variables, we had n points that were located in the space of individual R ^{m}. Each point was associated with a new point for which the coordinate on a factorial axis was a measurement of the correlation between the variable and the corresponding factor. In order to define a subspace of R ^{m} we sought unit vectors v _{α}. These were the eigenvectors of the matrix XX ^{T} in decreasing order of corresponding eigenvalues. The coordinates of the variable points on the axis α were the n components of the vector ϕ _{ α } = X ^{T} v _{ α }. We showed that the coordinate of a variable point on an axis was actually the correlation coefficient for this variable with the corresponding factor ψ _{ α }. Because the factorial axes were orthogonal pairs, we obtained a series of uncorrelated artificial variables called principal components, which synthesized the correlations of all the original variables.
In the space of dimension m, the distance between the pointvariables and the origin was equal to 1, and therefore, by projection on a factorial plane, variablespoints were part of a circle of radius 1, also known as the circle of correlations. These points were even closer to the edge of the circle as the variable point was wellrepresented by the factorial plane and thereby the variable was correlated with the two factors that made up the plane. Variables that were not located at the edge of the circle in a factorial plane were not correlated with the two corresponding factors and effectively were not useful for interpretation.
If we followed the first factorial plane, the coordinates of variablepoints in the plane were given by quantities denoted ϕ _{1}(j) and ϕ _{2}(j). Considering the values of ϕ _{ α }(j) for the first two axes, the distance from the center of the circle, {r}_{j}=\sqrt{{\varphi}_{1}^{2}\left(j\right)+{\varphi}_{2}^{2}\left(j\right)} was calculated and variables were sorted in descending order of r _{ j }.
Additional measures could be used to assist with the interpretation. In this regard, first the relative contribution of a variable to the inertia was explained by the axis α:
where ϕ _{ α }(j) represented the coordinate of the variable j on the axis α (Additional file 3) and second the quality of the representation of the variable j by its projection on the axis α:
where ‖x _{ j }‖ was the norm (i.e. length) of the vector variable j.
Hierarchical clustering on principal component
The simultaneous analysis of a principal component map and hierarchical clustering enriched the approach by representing the whole hierarchical tree in three dimensions on the principal component map [32], which was achieved by representing the centers of gravity of the partition (i.e. the highest nodes of the hierarchy).
Calculations were performed using MATLAB 6.1 (MathWorks, Inc. Natick, MA 01760 USA) and STATA 11 (StataCorp LP, College Station, TX 77845 USA).
Results
The average costs of sarcoma management reached €26,156 (SD18,190) for patients diagnosed and treated in RhôneAlpes (n = 58) and €24,986 (SD 24,575) for patients diagnosed and treated in Veneto (n = 161). The details of these mean costs of each stage of sarcoma management are shown in Table 2.
Table 3 reports data from Matrix A, which indicates the average of resources used and unit costs at the intersection of each column (16 areas of variability) and row (12 objects). In addition, the standardized data of Matrix X are reported in Additional file 4.
Cluster analysis
As shown in Additional file 1, the best cophenetic correlation coefficient was obtained with the Euclidean metric and the Average linkage (0.83). The hierarchical tree information was shown in Figure 2, where the new clusters that were obtained by cluster analysis are numbered from 13 to 23. In Figure 2, the numbers along the horizontal axis represent the indices of the objects in the original data set. The links between objects are represented as upside down Ushaped lines, with the height of the U indicates corresponding to the distance between the objects. The analysis shows 4 clusters:

(1)
cluster 5 only chemotherapy in France (object 5);

(2)
cluster 12 only followup with relapse in Italy (object 12);

(3)
cluster 18 including surgery in Italy (object 4), radiotherapy in Italy (object 8), diagnosis in Italy (object 2), followup without relapse in Italy (object 10), and chemotherapy in Italy (object 6);

(4)
cluster 20 including diagnosis in France (object 1), followup without relapse in France (object 9), radiotherapy in France (object 7), surgery in France (object 3), and followup with relapse in France (object 11).
The details of the linkage information, including identification and specification of the pair of objects that had been linked and the distances between these objects, are shown in Additional file 5.
The optimal number of clusters based on the use of RSQ, SPRSQ, RMSSTD and the pF is shown in Figure 1. According to the pseudoF statistics, the best choice was 4 clusters, which confirmed our interpretation based on the hierarchical tree.
Principal component analysis
Figure 3 shows the areas of variability (variables) in the correlation circle. The red circle of radius 0.8 drawn in the unit circle corresponds to the calculation of r _{ j } given in Additional file 6. This facilitates the identification of variables. Moreover we used CTR _{1}(j ) and CTR _{2}(j ) (Additional file 3) and co{s}_{1}^{2}\left(j\right), co{s}_{2}^{2}\left(j\right) (Additional file 7). Hence, referring to the previous graph one clearly characterize several groups for variables. Along axis 1, a group on the right including Unit cost of days of hospital admissions (area 10) and Unit cost of external consultations (area 12) can be identified, as well as another group on the left comprising Unit cost of radiotherapy sessions (area 14) and Unit cost of preparation for radiotherapy sessions (area 15). Along axis 2 there is only one group (on the top) that contains Quantity of chemotherapy drugs (area 8) and Unit cost of imaging (area 11). Other areas of variability (e.g. quantity of external consultations (area 4)) were too close to the center to be interpretable.
Figure 4 shows the projection of 12 objects on the map formed by the first two principal components, revealing four groups corresponding to the previously identified clusters. PCA also indicates that axis 1 opposes followup with relapse in Italy (object 12 in lefthand side) with followup with relapse in France (object 11 in righthand side). The projection of 12 objects on the map formed by the first three principal components is shown in Additional file 8. The inertia of the first three components corresponded to 59.43% of the total inertia instead of 44.76% for the two first components.
In addition, an analysis that takes into account the PCA distributions of both areas of variability and objects shows, as previous evidenced, an opposition between followup with relapse in France (object 11) and followup with relapse in Italy (object 12). Therefore, it is evident that this difference mainly results from unit cost of days of hospital admissions (area 10), unit cost of external consultations (area 12), unit cost of radiotherapy sessions (area 14), and unit cost of preparation for radiotherapy sessions (area 15). Moreover, a discrepancy is observed between diagnosis in Italy (object 2) and diagnosis in France (object 1), explaining that this difference is mostly due to quantity of biopsies (area 1) and unit cost of biopsies (area 9).
Even though we utilized the first two principle axes, we tried to go further. The initial table was of the size (n× m) = (12×16). We formed the matrix X of standardized data and diagonalized the correlation matrix Γ = X ^{T} × X. In effect, we had to find 16 eigenvalues. Based on the Kaiser criterion, we retained the principle components corresponding to eigenvalues above 1. In doing so, we had to retain 6 eigenvalues. Unfortunately, we can perform graphic representation in R ^{3} at the maximum.
Hierarchical clustering on principal component
Figure 5 displays the 3Dimensional representation of the hierarchical tree on the map produced by the first two principal components. The map shows that the four clusters are well separated on the first two principal components. Also, this graph enables visualization of the complementarity of the two methods.
Taken together, using this methodology, we were able to identify objects within our analysis that displayed high variability (i.e. lower transferability), which allowed us to distinguish areas that contributed to cost evaluation discrepancies. This study utilized both CA and PCA in order to evaluate the transferability of the results of a health economics evaluation between two countries.
Discussion
Discussion of results on variability in sarcoma management
Based on quantities of resources used and unit costs, the present study reveals a high discrepancy between France and Italy even though both countries reached a consensus in their clinical practice guidelines relating to all phases of sarcoma management (initial examination and diagnosis, histopathological report, surgery, chemotherapy, and radiation therapy), excluding followup after therapy [33],[34]. Differences in the quantity of resources used could be controlled through study design (e.g. multicenter randomized trials focused on economic evaluations). However, this was not possible in this study because data were retrospectively collected and were not obtained as part of a clinical trial dedicated to this question [20].
This study also showed differences in diagnosis between Italy and France, and this heterogeneity could be explained, according to PCA, by differences in unit cost of biopsies and in quantity of biopsies. The latter could be explained by Italy employing cytology biopsies before surgical ones. This difference in management, and also difference in costs, does not permit a consistent external validity of health economic evaluations in this phase of sarcoma management. The difference between followup with relapse in France and in Italy was explained by a difference in unit costs, which generally have a low transferability level compared to other data elements [35]. Differences in payment systems and incentives between both countries could be valid reasons for variability, especially between clusters 5, 12, 18, and 20 as stated by Barbieri [36]. In particular, object 5 in PCA analysis and cluster 23 in CA (chemotherapy in France) are explained by the higher cost of chemotherapy in France than in Italy, as evidenced also in Table 3. This could be due to efforts by the Region Veneto Health Directorate to increase economy and efficiency in the use of resources through a number of actions, for example, defining a sort of `threshold’ of appropriateness of chemotherapy provided through inpatient hospitalizations to promote the outpatient health care system [37] or a deep health technology assessment for high cost imaging (for example, PET) to offer examination only when appropriate [38].
As clinicians commonly have limited personal experience managing sarcoma outside of centers of excellence (due to rarity of the disease, variety of histological types, little graduate or postgraduate medical training, etc.), it might be interesting to analyze, using CA and PCA, how clinicians’ adherence versus nonadherence to practice guidelines can modify the hierarchical structure [39][41]. In this regard, based on six phases of management (diagnosis, surgery, chemotherapy, radiotherapy, followup with relapse, and followup without relapse), two regions (Veneto and RhôneAlpes), and compliance (or not) with clinical practice guidelines, we could generated 24 objects (6 × 2 × 2 = 24): compliant diagnosis in France (object 1); noncompliant diagnosis in France (object 2), etc. Those investigations should permit an even more precise assessment of barriers to the transferability of cost evaluations in this healthcare setting.
Discussion on new methodological approach to identify variability
The approach used is analytical, identifying the factors of variability and gathering them into homogeneous categories, thus making it possible to measure proximities either between objects (CA and PCA approaches) or between objects and areas of variability (PCA approach). The identification of the factors of variability and their regrouping into homogeneous categories (i.e. areas of variability) has already been studied in the literature. For example, the review of the literature carried out by Sculpher et al. shows that four groups are generally retained as the area of variability: the characteristics of the patients, the clinical parameters, the healthcare systems, and the socioeconomic aspects [4].
CA and PCA have already been used in the field of health economics [42][44]. However, measurement using formal statistical methods (CA and PCA), based on the unit costs and quantities of resources used during sarcoma management, has not been performed in the past to assess variability of data in cost evaluations. CA attempts to gain first order knowledge by partitioning data points into disjoint groups based on similarity, with dissimilar data points belonging to distinct clusters. Alternatively, PCA attempts to transform high dimensional data into lower dimensional data where coherent patterns can be detected more clearly [30]. CA and PCA were found to be very complementary tools to assess transferability of health cost evaluation across locations (Figure 5); especially since in this case Matrix A was a sparse matrix. Moreover, the two methods present good concordance. Recent research on data mining has demonstrated the possibility of presenting both methods simultaneously representing the 3Dimensional hierarchical tree [32]. Methods to assess the transferability of economic data are increasingly needed as the demand for economic evaluations across multiple countries often outstrips the availability of local data to support these evaluations.
Limitations of the study
Further research involving the application of CA and PCA to the assessment of microcost datasets is needed. It would be interesting to analyze the differences in cost evaluation and resources used for a single subtype of sarcoma histology or for the management of other more frequent cancers. This study only takes into account resources used and unit costs. In the future, it will be necessary to test this methodology with additional data elements, such as baseline risk, treatment effect, and health utilities in order to continue to assess the transferability of economics evaluations across locations. Potential towards health economics evaluations (e.g. multinational costeffectiveness analysis) which are different and more complex in comparison with cost studies hasn’t been taken into account in the present study.
Conclusions
CA and PCA provided a description of the variability in health cost evaluations between France and Italy. Indeed, using CA and PCA revealed the large spectrum of heterogeneity in sarcoma management. In future studies, regression methods could be applied after these methods to elucidate the determinants of the differences found with these analyses.
Authors’ contributions
LP, AB, GM, PSB, JYB, IRC designed the study, acquired and interpreted the clinical and cost data, undertook the statistical analyses, and prepared the manuscript. FD, PJP, CCR, FNG, AM, BF, FF, ML, VB, OC, DC participated in clinical data acquisition. JYB, CRR and IRC participated in general CONTICANET coordination. All authors read and approved the final manuscript.
Additional files
Abbreviations
 CA:

Cluster analysis
 CONTICANET:

Connective tissues cancers network
 PCA:

Principal component analysis
 pF:

pseudoF statistic
 RMSSTD:

The rootmeansquare standard deviation
 RSQ:

RSquare
 SPRSQ:

The semipartial Rsquared
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Acknowledgements
The authors thank EUROSARC (the European Union Seventh Framework Programme (FP7/20072013) under Grant Agreement n°278742), the Network of Excellence CONTICANET (contract code: FP018806), the French National Cancer Institute, the Canceropole Lyon Auvergne RhoneAlpes CLARA (contract code: 2010 ProCan IV2ERPCS), Merck Serono, DEVweCAN, LYRIC, and DAM’ Association. The authors also thank Giuseppe Zamengo (Direzione Regionale Risorse Socio Sanitarie, Servizio Sistema Informativo Socio Sanitario e Tecnologie Informatiche, Regione Veneto), Pr Cyrille Colin (Direction de l’information hospitalière, Hospices Civils de Lyon), Dr Frédéric Gomez (Direction de l’information hospitalière, Centre Léon Bérard), Mr Nicolas Caquot (Direction administrative et financière, Centre Léon Bérard). Sophie Minguet assisted with the final editing of the manuscript. The authors would like to thank the referees for their insightful comments and suggestions.
Funding sources
EUROSARC European Union Seventh Framework Programme (FP7/20072013) under Grant Agreement n°278742; The Network of Excellence CONTICANET (contract code: FP018806); DEVweCAN, LYRIC (the French National Cancer Institute INCA04664); The Canceropole Lyon Auvergne RhoneAlpes CLARA (contract code: 2010 ProCan IV2ERPCS); Merck Serono; DAM’s association (patient advocacy group).
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Additional file 1: The values c of the cophenetic correlation coefficient according to metric and linkage methods. (DOCX 33 KB)
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Additional file 8: The projection of the 12 objects onto the map formed by the first three dimensions of space. (DOCX 229 KB)
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Perrier, L., Buja, A., Mastrangelo, G. et al. Transferability of health cost evaluation across locations in oncology: cluster and principal component analysis as an explorative tool. BMC Health Serv Res 14, 537 (2014). https://doi.org/10.1186/s129130140537x
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DOI: https://doi.org/10.1186/s129130140537x