09.02.2021 | Ausgabe 3/2021 Open Access

# Connectedness versus diversification: two sides of the same coin

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## 1 Introduction

The idea that risk reduction for an investment portfolio can be achieved through a diversification approach is central in the Markowitz model, see Markowitz [
19], and one of the principal reasons of its popularity. There is a wide consensus on the risk reduction properties of the diversification, both from practitioners and academics. The qualitative definition of diversification is natural for portfolio managers: an investment portfolio is well diversified when it is not exposed to individual shocks occurring to its constituents. The formal definition of diversification remains an elusive concept and it is hardly made explicit in portfolio optimization studies, with an exception for the paper by Meucci [
20] and related studies. In its paper, Meucci proposes to use principal component analysis to extract uncorrelated risk factors starting from the underlying assets.

The vagueness of its definition gave rise to a huge literature focusing on different aspects of diversification. Many different approaches for diversification based portfolio strategies have been studied in the literature: among the others, we recall the naive diversification strategy and the measurement of its out of sample performance, see DeMiguel et al. [
7], the equally risk contribution diversification strategy, see Roncalli and Weisang [
23] and Qian [
22], the application of the approach proposed by Meucci, see Lohre et al. [
17], the determination of maximum diversification portfolios, see Choueifaty and Coignard [
5], the investment strategy based on the maximization of the diversification ratio, see Choueifaty et al. [
6], the strategy based on the generalized Rao’s entropy used as a diversification measure, see Choueifaty et al. [
6]. Moreover, the literature presents further approaches that relate the diversification to different aspects of portfolio composition, like sector diversification and geographical diversification, see for example Hauser and Vermeersch [
14] and Diamond and Abdullah [
8], or product based diversification, see for example Bernardi et al. [
1], for the diversification approach based on commodities risk factors. In this paper we refer to the axiomatic definition of coherent diversification measures proposed by Koumou and Dionne [
16].

Anzeige

While the idea of diversification approximately dates back to 1950s, the concept of connectedness is relatively new. It has been first introduced by Diebold and Yilmaz, see Diebold and Yilmaz [
9], and successively developed in subsequent papers, see among the others Diebold and Yilmaz [
10] and Diebold and Yilmaz [
11], in which the authors well describe the concept of connectedness, pointing out the lack of a formal definition and the resulting vagueness of the notion. Recently, an attempt to formalize the concept of connectedness through an axiomatic approach has been proposed in Maggi et al. [
18]. The idea behind connectedness is to measure the degree of the inter-relations and the inter-dependencies between the components of a whole system and to summarize the information in a single number. Despite its potential generality, restricting to the financial context, a high connectedness reflects a strong interdependence between the elements of the system. This interpretation highlights the intuitive relation between connectedness and systemic risk. For a comprehensive review of the measures proposed in the literature for systemic risk analysis we refer to the survey by Bisias et al. [
4].

In the context of portfolio theory, diversification is usually achieved through the computation of the optimal weights to invest in. On the opposite, connectedness is not directly related to portfolio theory and portfolio weights are not considered when evaluating the connectedness of a market or an economic system or even the assets of a portfolio. Despite the differences and the distinctive features among connectedness and diversification, in this paper we aim at investigate and highlight the deep relation between the two concepts.

An important similarity can be found in the role of correlation. As pointed out in Diebold and Yilmaz [
11], in the literature on connectedness the use of correlation-based measures is widespread and the concept of connectedness may be seen as a generalization of the concept of correlation while, on the other hand, correlation is the standard base for the evaluation of diversification. One further link between connectedness and diversification can be found in the role of the eigenvalues in both fields, see for instance Meucci [
20] and Maggi et al. [
18], where the eigenvalues are used to evaluate both diversification and connectedness.

In accordance to standard portfolio theory asserting that the portfolio risk can be decomposed into its systematic and idiosyncratic components, diversification is geared at eliminating the idiosyncratic risk while connectedness estimates the systemic risk component. In this framework, the relation between the two concepts is immediate and connectedness can be thought as the complement of the diversification with respect to the the total risk of a portfolio. Referring to the idiosyncratic and systemic components of the risk, it is useful to interpret the monotonicity properties of the two measures with respect to the size of the portfolio; in particular, diversification improves with large portfolios while connectedness, representing the systemic component, is not positively affected by a growing number of assets. We will show that a high level of connectedness corresponds to a reduced possibility to build a well diversified portfolio. On the opposite, the possibility to build a well diversified portfolio is related to a low level of connectedness between the assets, i.e. the assets provide good opportunities of diversification.

Anzeige

In this paper, in order to highlight the similarities between connectedness and diversification, we explicitly introduce the weights in the computation of connectedness, generalizing its definition and showing that standard measures of connectedness can be related to the special case of the equally weighted portfolios. Further, we effectively analyze this correspondence by comparing the axiomatic frameworks of the Proper Measures of Connectedness (PMCs) and the Coherent Portfolio Diversification Measures (CPDMs), see Maggi et al. [
18] and Koumou and Dionne [
16] respectively. We note that, due to the peculiarities of the two settings, the requirements for PMCs are less restrictive than the ones for CPDMs. As a consequence, a specific PMC needs to verify some additional properties to be properly related to a CPDM.

Our approach is general. We introduce a suitable function
\(\mathcal F\) and prove that, if applied to a subclass of PMCs verifying given additional properties, such as, for example, quasi-convexity and homogeneity, it transforms such measures into CPDMs. Then, we consider a selection of four PMCs, the Maximum Variance Inflation Factor (M-VIF), see Belsey et al. [
2], the Power Mean measures
\(\mu _k^1\), see Maggi et al. [
18], the Market Rank Indicator, see Figini et al. [
12] and the Cumulative Risk Fraction
\(h_k\), see Billio et al. [
3], and we apply
\(\mathcal F\) defining four original diversification measures. We prove in details that
\(\mathcal F_{\text {M-VIF}}\) is a CPDM and show that the measures of diversification
\(\mathcal F_{\mu _k^1}\),
\(\mathcal F_{s_k}\) and
\(\mathcal F_{h_k}\) partially verify the theoretical requirements of CPDMs.

The paper is organized as follows: in Sect.
2 we recall the axiomatic frameworks of PMCs and CPDMs; in Sect.
3 we introduce the function
\(\mathcal F\) providing the relationship between the concepts of connectedness and diversification, dwelling on the additional required properties on PMCs necessary to construct a CPDM; in Sect.
4 we apply
\(\mathcal F\) to a selection of PMCs and prove the properties they verify as induced measures of diversification; finally, in Sect.
5 we discuss the proposed results.

## 2 Connectedness and diversification: axiomatic definitions

In this section we recall the general notions of Proper Measures of Connectedness (PMCs) and Coherent Diversification Measures (CDMs) briefly specifying the economic interpretation of the theoretical properties required for the axiomatic definition of the two families of measures; for a more detailed description we refer to Maggi et al. [
18] and Koumou and Dionne [
16] respectively. In order to compare the measures of connectedness and diversification in a meaningful perspective, we refer to the portfolio allocation scheme, where the CPDMs have been principally developed.

### 2.1 Notation and preliminaries

Let
\(m \ge n \ge 2\), let
\(\mathrm{Mat}_{m \times n}\) be the set of
\(m \times n\) real matrices and
\({\mathcal M}_{m \times n}\) be the subset of
\(\mathrm{Mat}_{m \times n}\) containing all the full-rank matrices, i.e.
\(\mathrm{rank}(A) = n,\ \forall A \in {\mathcal M}_{m \times n}\). We indicate with
\(\mathbf {0}_{m \times n}\) and
\(\mathbf {1}_{m \times n}\) the
\(m \times n\) matrices whose elements are all equal to zero and one respectively. For brevity, we will also use the simpler notation
\(\mathbf {1}_n\), or even
\(\mathbf {1}\) if the size of the vector is clear from the context, to denote the vector
\(\mathbf {1}_{n \times 1}\). Throughout the paper, we will interpret the entries of the column vectors
\(A^j\), with
\(j = 1, \ldots , n\), of any matrix
\(A=(a_{ij})\) as the historical observations of the
jth return of the portfolio, so that the
\(m \times n\) matrix
A is the usual matrix of portfolio returns with
m historical data and
n assets. We denote by
\(\overline{A^j}\) the mean of
\(A^j\) and let
\(\overline{A}=(\overline{A^1} {\varvec{1}}_{m \times 1},\ldots ,\overline{A^n} {\varvec{1}}_{m \times 1})\);
\(\overline{A}\) contains the averages of the historical returns of the assets in the portfolio. We let
\(A^t\) be the transposed of
A and
\(\sigma _1(A) \ge \ldots \ge \sigma _r(A)>0\), with
\(r=\mathrm{rank}(A)\), be the singular values of
A listed as usual in nonincreasing order; further, for any
\(\alpha \in \mathbb R\), we denote by
\(A+\alpha \) and
\(\alpha A\) the
\(m \times n\) matrices whose (
i,
j) entry is
\(a_{ij}+\alpha \) and
\(\alpha a_{ij}\), respectively. We let
\(P=(p_1,\ldots ,p_r)\) be the list of pivots obtained by the classical Gauss-Jordan elimination applied to
A and
\(A^P = (A^{p_1},\ldots ,A^{p_r}) \in \mathcal M_{m \times r}\). We denote by
\(\rho (\cdot , \cdot )\) the Pearson correlation coefficient, by
\(\langle \cdot ,\cdot \rangle \) the standard scalar product and by
\(\Vert \cdot \Vert \) the Euclidean norm of
\(\mathbb R^n\). Finally, we let
\(\mathbb W_n=\{\varvec{w}=(w_1,\ldots ,w_n)^t \in \mathbb R_{\ge 0}^n \,|\, \sum _{j=1}^n w_j=1\}\) be the set of long-only portfolios associated to
A, so that
\(w_j\) is the weight of asset
\(A^j\) in the portfolio
\(\varvec{w}\), and we define
\(W=\text {diag}({\varvec{w}}) \in \mathrm{Mat}_{n \times n}\) as the diagonal matrix with elements
\(w_1,\ldots ,w_n\). A portfolio made up of a single asset
j is denoted by
\({\varvec{e}}_j^t\), where
\({\varvec{e}}_1,\ldots , {\varvec{e}}_n\) is the standard basis of
\(\mathbb R^n\).

We denote by
\(\mathcal H^{m,n}\) the set of all positive real-valued functions defined over the set of matrices
\(\text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\) and by
\(\mathcal H_{{\varvec{w}}}^{m,n}\) the set of all positive real-valued functions defined over
\(\mathbb W_n \times \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\). In the following definition we list some properties of functions belonging to
\(\mathcal H^{m,n}\).

Definition 1

Let
\(g \in \mathcal H^{m,n}\); then
g is said to be

(i)

invariant under independent translations if
\(g(A+B) = g(A)\) for each nonzero
\(A \in \text {Mat}_{m \times n}\) having no rows and no columns equal to
\(\mathbf {1}_{1\times n}\) and
\(\mathbf {1}_{m\times 1}\) respectively, and
\(B=(b_{ij}) \in \text {Mat}_{m \times n}\) such that
\(b_{ij}=\beta _j \in \mathbb R\) for each
\(i=1,\ldots ,m\) and
\(j=1,\ldots ,n\);

(ii)

invariant for size if
\(g(A | b) = g(A)\) for each nonzero
\(A \in \text {Mat}_{m \times n}\) and
\(b \in \text {Mat}_{m \times 1}\) such that
\(\mathrm{rank}(A | b) = \mathrm{rank}(A)\);

(iii)

invariant under columns permutations if
\(g(A \varPi ) = g(A)\) for each
\(A \in \mathcal {M}_{m \times n}\) and for any permutation matrix
\(\varPi \in \mathrm{Mat}_{n \times n}\);

(iv)

invariant under one scalar multiplication if
\(g(A^1,\ldots , \alpha A^k,\ldots ,A^n)=g(A)\) for each nonzero
\(A \in \text {Mat}_{m \times n}\),
\(\alpha >0\) and
\(k \in \{1,\ldots ,n\}\);

(v)

homogeneous of degree 0 if
\(g(\alpha A)=g(A)\) for each nonzero
\(A \in \text {Mat}_{m \times n}\) and
\(\alpha >0\);

(vi)

quasi-convex if
\(g(\alpha A + (1-\alpha )B) \le \max \{g(A), g(B)\}\) for each
\(A,B \in {\mathcal M}_{m \times n}\) and
\(\alpha \in [0,1]\).

Remark 1

It is immediate to observe that the invariance under one scalar multiplication is a very strong property which implies that the function is invariant under (even different) simultaneous scalar multiplication of each column. Further, in particular, it implies the degree 0 homogeneity property.

### 2.2 Connectedness

Definition 2

(PMCs) A real-valued function
\(C: {\mathcal M}_{m \times n} \rightarrow \mathbb R\), defined by
C(
A) for each
\(A \in {\mathcal M}_{m \times n}\) is a
Proper Measure of Connectedness (PMC) if it satisfies the following minimal properties
C1,
C2,
C3 and
C4.

C1.

\(C(A) \ge 0\), for any
\(A \in {\mathcal M}_{m \times n}\).

C2.

C(
A) is invariant for any permutation of the columns of
\(A \in {\mathcal M}_{m \times n}\).

C3.

\(C(A)>C(B)\) if and only if
\(C(\alpha A)>C(\alpha B)\), for any
\(A, B \in {\mathcal M}_{m \times n}\) and
\(\alpha >0\).

C4.

Let
\(a_1, a_2, a_3 \in {\mathcal M}_{m \times 1}\), with
\(\Vert a_2\Vert =\Vert a_3\Vert \) and
\(\langle \mathbf {1},a_2\rangle =\langle \mathbf {1},a_3\rangle =0\). If
\(|\rho (a_1,a_2)| \ge |\rho (a_1,a_3)|\) then
\(C((a_1,a_2)) \ge C((a_1, a_3))\) where, with a small abuse of notation, we assume that
\((a_1,a_2), (a_1, a_3) \in {\mathcal M}_{m \times 2}\).

It is useful to observe that if
C satisfies property (
v) of Definition
1, then
C satisfies property
C3.

In the financial context, the minimal properties required in Definition
2 for a PMC are intuitive. If we exclude property
C1 that is a pure technical condition, a PMC is not affected by the order the assets are considered, see property
C2. Property
C3 requires that a positive rescaling in the data does not significantly impact the structure of connectedness. Finally, with property
C4, a PMC is required to embody at least the information of the correlation structure of the data so that a higher correlation results in a higher connectedness. The opposite implication does not hold; an increase in the value of connectedness could depend on different causes than an increase in the value of correlation among the data.

Definition
2 provides the general notion of PMCs, as given in (Maggi et al., [
18]). In this paper, in order to use PMCs in the context of standard portfolio theory, we will consider connectedness measures defined on matrices
AW, where
\(W=\text {diag}({\varvec{w}})\) is the diagonal matrix associated to a tuple of portfolio weights
\({\varvec{w}} \in \mathbb W_n\). In this way, Definition
2 boils down to the standard definition of PMCs when the function
C is homogeneous of degree 0 and the considered portfolio is
\(\frac{1}{n}\mathbf {1}\), that is the equally weighted portfolio.

### 2.3 Diversification

In the following definition we recall the Coherent Portfolio Diversification Measures (CPDMs).

Definition 3

(CPDMs) A real-valued function
\(\varPhi ^{(m,n)}: \mathbb W_n \times \mathrm{Mat}_{m \times n} \rightarrow \mathbb R\), simply denoted by
\(\varPhi \) when no confusion arises, is a
Coherent Portfolio Diversification Measure (CPDM) if it satisfies the following axioms
D1,
D2,
D3,
D4,
D5,
D6,
D7,
D8 and
D9.

D1.

(Quasi-concavity) For any
\({\varvec{w}}_1, {\varvec{w}}_2 \in \mathbb W_n\) and
\(\alpha \in [0,1]\) it holds that
\(\varPhi (\alpha \varvec{w}_1+(1-\alpha ){\varvec{w}}_2, A) \ge \min \{\varPhi (\varvec{w}_1, A), \varPhi ({\varvec{w}}_2, A)\}\), with strict inequality for at least one value of
\(\alpha \).

D2.

(Size degeneracy) There is a constant
\(\underline{\varPhi } \in \mathbb R\) such that
\(\varPhi ({\varvec{e}}_j, A) = \underline{\varPhi }\), for each
\(j = 1,\ldots ,n\).

D3.

(Risk degeneracy) Let
A be such that
\(A^i=A^j\) for each
\(i,j=1,\ldots ,n\); then, there is a constant
\(\underline{\varPhi } \in \mathbb R\) such that
\(\varPhi ({\varvec{w}}, A) = \underline{\varPhi }\) for each
\({\varvec{w}} \in \mathbb W_n\).

D4.

(Reverse risk degeneracy) For any
\({\varvec{w}} \in \mathbb W_n\) such that
\({\varvec{w}} \ne {\varvec{e}}_j\),
\(j=1,\ldots ,n\), and
\(w_i>0\),
\(i=1,\ldots ,n\), we consider the equation
\(\varPhi ({\varvec{w}}, A) = \underline{\varPhi }\) in the variable
\(A \in \mathrm{Mat}_{m \times n}\) and assume that a solution
\(A^*\) exists. Then
\(A^*\) is lower comonotonic.

D5.

(Duplication invariance) Let
\(k \in \{1,\ldots ,n\}\) and
\(A^+=(A\,|\,A^k) \in \mathrm{Mat}_{m \times (n+1)}\). Then
\(\varPhi ({\varvec{w}}^+, A^+)=\varPhi ({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\) and
\({\varvec{w}}^+ \in \mathbb W_{n+1}\) such that
\(w^+_j=w_j\), for each
\(j=1,\ldots ,n\),
\(j \ne k\), and
\(w^+_k + w^+_{n+1} = w_k\).

D6.

(Size monotonicity) Let
\(A^+=(A\,|\,A^{n+1}) \in \mathrm{Mat}_{m \times (n+1)}\), with
\(A^{n+1} \ne A^j\) for each
\(j=1,\ldots ,n\). Then
\(\varPhi ({\varvec{w}}^+, A^+) \ge \varPhi ({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\) and
\({\varvec{w}}^+ \in \mathbb W_{n+1}\) such that
\((w^+_1,\ldots ,w^+_n)\) is proportional to
\({\varvec{w}}\).

D7.

(Translation invariance) Let
\(\alpha \in \mathbb R\); then
\(\varPhi ({\varvec{w}}, A+ \alpha ) = \varPhi ({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

D8.

(Homogeneity) Let
\(\alpha \ge 0\); then there exists
\(r \in \mathbb R\) such that
\(\varPhi ({\varvec{w}}, \alpha A) = \alpha ^r \varPhi ({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

D9.

(Symmetry) Let
\(\varPi \in \mathrm{Mat}_{n \times n}\) be a permutation matrix; then
\(\varPhi ({\varvec{w}}\varPi , A \varPi ) = \varPhi ({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

In Koumou and Dionne [
16], axiom
D1 requires quasi-convexity or, alternatively, convexity. Considering that convexity implies quasi-convexity, we preferred to directly require quasi-convexity.

In the financial context, the minimal properties for a CPDM listed in Definition
3 have the following economic interpretation. The preference towards diversification such that holding different assets increases diversification is translated by property
D1. Property
D2, size degeneracy, reflects that
single asset portfolios are equivalent to the minimum level of diversification. Properties
D3 and
D4, risk degeneracy and reverse risk degeneracy, respectively state that including perfect similar assets in a portfolio do not help diversification and that a portfolio composed by assets with independent returns and single asset portfolios do not have the same level of diversification. Property
D5, duplication invariance, is required to avoid that diversification measurement is affected by multiple representative assets. Property
D6, size monotonicity, reflects the relation between portfolio diversification and the number of assets in the portfolio. Adding a deterministic cash return does not impact portfolio diversification: this idea is described by property
D7. Diversification is not affected by scalar transformations of the input data, see property
D8 about homogeneity. Finally, as in the context of connectedness, diversification is required to be independent from any permutation of the assets in a portfolio, see property
D9 about symmetry.

## 3 From connectedness to diversification

In this section we propose a method to construct original portfolio diversification measures starting from given PMCs. In order to explicitly define a subclass of CPDMs we need to require the PMCs to verify some extra properties, restricting the class of PMCs that are of potential interest. The passage from connectedness to diversification is possible through the use of a specific transformation function
\(\mathcal F: \mathcal H^{m,n} \rightarrow \mathcal H^{m,n}_{{\varvec{w}}}\) defined as follows.

Definition 4

(Transformation function) Let
\(C \in \mathcal H^{m,n}\) and
\(f_C \in \mathcal H^{m,n}_{\varvec{w}}\) be the function defined by:
for each
\({\varvec{w}} \in \mathbb W_n\) and
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\), where
\(W=\text {diag}({\varvec{w}}) \in \text {Mat}_{n \times n}\).

$$\begin{aligned} f_C({\varvec{w}}, A) = \mathrm{rank}(AW) + \frac{1}{C(AW)}-1 \end{aligned}$$

The
transformation function
\(\mathcal F: \mathcal H^{m,n} \rightarrow \mathcal H^{m,n}_{\varvec{w}}\) is defined by
\(\mathcal F(C)=\mathcal F_C \in \mathcal H^{m,n}_{\varvec{w}}\), for each
\(C \in \mathcal H^{m,n}\), where
\(\mathcal F_C\) acts on
\(\mathbb W_n \times \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\) as follows:
for each
\({\varvec{w}} \in \mathbb W_n\) and
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\).

$$\begin{aligned} \begin{array}{lll} \mathcal F_C({\varvec{w}}, A)= & {} 1 - \frac{1}{f_C({\varvec{w}},A)} \end{array} \end{aligned}$$

Note that in the rest of the paper we will only consider the nontrivial and meaningful case
\(\mathrm{rank}(AW)>0\). Intuitively, the behaviour of
\(\mathcal F_C\) agrees with the distinguishing feature of diversification: indeed, if we consider the simplest case of the equally weighted portfolios,
\(\mathcal F_C\) decreases as the function
C increases, which highlights the main relationship between the notions of diversification and connectedness (if the overall connectedness between the assets increases, the diversification opportunities when creating a portfolio with these assets are expected to reduce).

The following proposition gathers some basic properties on
\(\mathcal F_C\).

Proposition 1

Let
C be a function of
\(\mathcal H^{m,n}\) that assumes values in
\([1,+\infty )\). For each nonzero
\(A, A_1, A_2 \in \text {Mat}_{m \times n}\) and
\({\varvec{w}}, {\varvec{w}_1}, {\varvec{w}_2} \in \mathbb W_n\), with
\(W=\text {diag}({\varvec{w}}), W_1=\text {diag}({\varvec{w}_1}), W_2=\text {diag}({\varvec{w}_2}) \in \text {Mat}_{n \times n}\), the following properties hold.

1.

\(\mathcal F_C({\varvec{w}}, A)=0\) if and only if
\(\mathrm{rank}(AW)=1\) (and
\(C(AW)=1\));

2.

\(\mathcal F_C({\varvec{w}}, A) \in [0,1)\);

3.

\(1-\frac{1}{\mathrm{rank}(AW)-1} < \mathcal F_C({\varvec{w}}, A) \le 1-\frac{1}{\mathrm{rank}(AW)}\);

4.

if
\(\mathrm{rank}(A_1 W_1)< \mathrm{rank}(A_2 W_2)\) then
\(\mathcal F_C({\varvec{w}_1}, A_1)<\mathcal F_C({\varvec{w}_2}, A_2)\);

5.

if
\(w_j>0\), for each
\(j=1,\ldots ,n\), then
\(A^*\) is a solution of the equation
\(\mathcal F_C({\varvec{w}}, A)=0\) if and only if
\(\mathrm{rank}(A^*)=1\).

Proof

1.

The condition
\(\mathcal F_C({\varvec{w}}, A)=0\) is equivalent to the equality
\(f_C({\varvec{w}}, A)=\mathrm{rank}(AW) + \frac{1}{C(AW)}-1=1\); using the assumptions on the function
C we have
which yields
\(\mathrm{rank}(AW)=1\) and consequently
\(C(AW)=1\). On the other hand, imposing the positivity of the function
\(\mathcal F_C\), the condition
\(\mathrm{rank}(AW)=1\) implies that
\(C(AW)=1\), and so
\(\mathcal F_C({\varvec{w}}, A)=0\), so item
1 is proved.

$$\begin{aligned} \mathrm{rank}(AW)-1<f_C({\varvec{w}}, A) \le \mathrm{rank}(AW), \end{aligned}$$

(1)

2.

From now on, we consider the case
\(\mathrm{rank}(AW)\ge 2\). Following the hypothesis on the function
C we have
\(f_C({\varvec{w}}, A)>1\), therefore item
2 is proved.

4.

The hypothesis of item
4 yields
\(\mathrm{rank}(A_1 W_1)\le \mathrm{rank}(A_2 W_2)-1\) so, using item
3, we have:
therefore item
4 is proved.

$$\begin{aligned} \mathcal F_C({\varvec{w}_1}, A_1) \le 1-\frac{1}{\mathrm{rank}(A_1 W_1)} \le 1-\frac{1}{\mathrm{rank}(A_2 W_2)-1} < \mathcal F_C({\varvec{w}_2}, A_2), \end{aligned}$$

5.

From item
1, any solution
\(A^*\) of the equation
\(\mathcal F_C({\varvec{w}}, A)=0\) satisfies
\(\mathrm{rank}(A^*W)=1\). Since, by hypothesis,
\(\mathrm{rank}(W)=n\), Sylvester inequality, see (Horn and Johnson, [
15, Section 0.4.5]), yields
\(1=\mathrm{rank}(A^*W)\ge \mathrm{rank}(A^*) +n-n = \mathrm{rank}(A^*)\), therefore item
5 is proved.

We now provide a deeper characterization of
\(\mathcal F_C\) on the base of additional properties required for
C. To this end, we need to introduce the following technical lemma yielding useful features of the rank operator in order to investigate the concavity properties of
\(\mathcal F_C\).

Lemma 1

Let
\(A \in {\mathcal M}_{m \times n}\) and
\({\varvec{w}_1}, {\varvec{w}_2} \in \mathbb W_n\), with
\(W_1=\text {diag}({\varvec{w}_1}), W_2=\text {diag}({\varvec{w}_2}) \in \text {Mat}_{n \times n}\). For any
\(\alpha \in (0,1)\), the following result holds:
with strict inequality if and only if
\(I_k \subsetneq I_1 \cup I_2 \),
\(k=1,2\), where
\(I_k=\{j \in \{1,\ldots ,n\} \;|\, w_{kj} >0\}\).

$$\begin{aligned} \mathrm{rank}(\alpha A W_1 + (1-\alpha )A W_2) \ge \max \{\mathrm{rank}(A W_1), \mathrm{rank}(A W_2)\}, \end{aligned}$$

Proof

Let
\(W_\alpha =\alpha W_1 + (1-\alpha )W_2 \in \text {Mat}_{m \times n}\) and
\(A W_\alpha = \alpha A W_1 + (1-\alpha )A W_2\). Since
\(\mathrm{rank}(A)=n\), Sylvester inequality, see Horn and Johnson [
15, Section 0.4.5], yields the following equalities
\(\mathrm{rank}(A W_1)=\mathrm{rank}(W_1)\) and
\(\mathrm{rank}(A W_2)=\mathrm{rank}(W_2)\). Further,
\(W_\alpha \) is a diagonal matrix whose entries are the strictly convex combinations of the corresponding elements of
\(W_1\) and
\(W_2\), so that its strictly positive entries are indexed by
\(I_1 \cup I_2\). It easily follows that
with strict inequality if and only if
\(I_k \subsetneq I_1 \cup I_2\), for each
\(k=1,2\). Therefore, combining (
2) and (
3), the result follows.
\(\square \)

$$\begin{aligned} \mathrm{rank}(A W_\alpha )=\mathrm{rank}(W_\alpha ), \end{aligned}$$

(2)

$$\begin{aligned} \mathrm{rank}(W_\alpha )\ge \max \{\mathrm{rank}(W_1), \mathrm{rank}(W_2)\}=\max \{\mathrm{rank}(AW_1), \mathrm{rank}(AW_2)\} \end{aligned}$$

(3)

Corollary 1

Under the hypotheses of Lemma
1, if either
\(W_1\) or
\(W_2\) is full-rank, then
\(\alpha A W_1 + (1-\alpha )A W_2\) is full-rank for each
\(\alpha \in (0,1)\).

Remark 2

The result of Lemma
1 can be easily transformed in terms of concavity by simply extending it to the case
\(\alpha \in [0,1]\). Indeed, using the notation of Lemma
1, for any
\(\alpha \in [0,1]\) the
\(\mathrm{rank}\) operator satisfies:
with strict inequality for some value of
\(\alpha \in (0,1)\) if and only if
\(I_k \subsetneq I_1 \cup I_2\),
\(k=1,2\). We conclude that the
\(\mathrm{rank}\) operator is a is a quasi-concave function.

$$\begin{aligned} \mathrm{rank}(\alpha A W_1 + (1-\alpha )A W_2) \ge \min \{\mathrm{rank}(A W_1), \mathrm{rank}(A W_2)\} \end{aligned}$$

On the base of the previous results, the following proposition highlights important concavity properties of the function
\(\mathcal F_C\).

Proposition 2

(Quasi-concavity) Let
C be a function of
\(\mathcal H^{m,n}\) which assumes values in
\([1,+\infty )\) and satisfying property (vi) of Definition
1. Then,
\(\mathcal F_C\) is a quasi-concave function of
\(\mathcal H^{m,n}\), that is for each nonzero
\(A \in \text {Mat}_{m \times n}\),
\(\alpha \in [0,1]\),
\({\varvec{w}_1}, {\varvec{w}_2} \in \mathbb W_n\), the following result holds:
with strict inequality for at least one value of
\(\alpha \in (0,1)\) when
\(I_k \subsetneq I_1 \cup I_2 \),
\(k=1,2\), where
\(I_k=\{j \in \{1,\ldots ,n\} \;|\, w_{kj} >0\}\).

$$\begin{aligned} \mathcal F_C(\alpha {\varvec{w}_1} + (1-\alpha ){\varvec{w}_2}, A) \ge \min \{\mathcal F_C({\varvec{w}_1}, A), \mathcal F_C({\varvec{w}_2}, A)\}, \end{aligned}$$

Proof

Let
\(W_1=\text {diag}({\varvec{w}_1}), W_2=\text {diag}({\varvec{w}_2}) \in \text {Mat}_{n \times n}\). The cases
\(\alpha =0\) and
\(\alpha =1\) are trivially verified. Let
\(\alpha \in (0,1)\) and let
\(I_k=\{j \in \{1,\ldots ,n\} \;|\, w_{kj} >0\}\), with
\(k=1,2\). If
\(I_k \subsetneq I_1 \cup I_2 \), for each
\(k=1,2\), then Lemma
1 yields
\(\mathrm{rank}(\alpha A W_1 + (1-\alpha )A W_2) > \max \{\mathrm{rank}(A W_1), \mathrm{rank}(A W_2)\}\), and applying Proposition
1, item
4, it follows:
Otherwise, assume that one of
\(I_k\),
\(k=1,2\), is such that
\(I_k=I_1 \cup I_2\). W.l.o.g. we assume that
\(k=1\), so that
\(I_2 \subseteq I_1\). Assume that
\(I_2 \subsetneq I_1\). Lemma
1 yields
\(\mathrm{rank}(\alpha A W_1 + (1-\alpha )A W_2) = \mathrm{rank}(A W_1) > \mathrm{rank}(A W_2)\) and applying Proposition
1, item
4, it follows
\(\mathcal F_C({\varvec{w}_1}, A) > \mathcal F_C({\varvec{w}_2}, A)\). Therefore, letting
\(W_\alpha =\alpha W_1 + (1-\alpha )W_2\) and using Proposition
1, item 3, we get
which yields
\(\mathcal F_C(\alpha {\varvec{w}_1} + (1-\alpha ){\varvec{w}_2}, A) \ge \min \{\mathcal F_C({\varvec{w}_1}, A), \mathcal F_C({\varvec{w}_2}, A)\}\).

$$\begin{aligned} \mathcal F_C(\alpha {\varvec{w}_1} + (1-\alpha ){\varvec{w}_2}, A) > \max \{\mathcal F_C({\varvec{w}_1}, A), \mathcal F_C({\varvec{w}_2}, A)\}. \end{aligned}$$

$$\begin{aligned} f_C(\alpha {\varvec{w}_1}+(1-\alpha ){\varvec{w}_2}, A)= & {} \mathrm{rank}(AW_\alpha )+\frac{1}{C(A W_\alpha )}-1 \\= & {} \mathrm{rank}(AW_1)+\frac{1}{C(A W_\alpha )}-1\\> & {} \mathrm{rank}(AW_1)-1 \ge \mathrm{rank}(AW_2)\\\ge & {} \mathrm{rank}(AW_2)+\frac{1}{C(AW_2)} -1 = f_C({\varvec{w}_2}, A), \end{aligned}$$

Finally, if
\(I_2 = I_1\), Lemma
1 assures that
\(\mathrm{rank}(\alpha A W_1 + (1-\alpha )A W_2) = \mathrm{rank}(A W_1) =\mathrm{rank}(A W_2)\); exploiting the quasi-convexity of
C we get
which yields
\(\mathcal F_C(\alpha {\varvec{w}_1} + (1-\alpha ){\varvec{w}_2}, A) \ge \min \{\mathcal F_C({\varvec{w}_1}, A), \mathcal F_C({\varvec{w}_2}, A)\}\).
\(\square \)

$$\begin{aligned} f_C(\alpha {\varvec{w}_1}+(1-\alpha ){\varvec{w}_2}, A)= & {} \mathrm{rank}(A W_i)+\frac{1}{C(\alpha AW_1 +(1-\alpha )A W_2)}-1\\\ge & {} \mathrm{rank}(A W_i) +\frac{1}{\max \{C(A W_1), C(AW_2)\}}-1 \\= & {} \min \{ f_C({\varvec{w}_1}, A), f_C({\varvec{w}_2}, A)\}, \end{aligned}$$

In the final part of the section we enumerate the technical results for additional properties on the function
\(\mathcal F_C\). We provide the sufficient conditions the connectedness measure
C needs to verify in order to define a CPDM through
\(\mathcal F_C\). In particular, Proposition
3 proves the Duplication invariance, Proposition
4 the Size monotonicity, Proposition
5 the Translation invariance, Proposition
6 the Homogeneity and Proposition
7 the Symmetry (see also CPDMs axioms, Section
2).

Proposition 3

(Duplication invariance) Let
C be a function of
\(\mathcal H^{m,n}\) that satisfies properties (ii), (iii), (iv) of Definition
1. Let
\(A \in \text {Mat}_{m \times n}\) be a nonzero matrix,
\(k \in \{1,\ldots ,n\}\) and
\(A^+=(A\,|\,A^k) \in \mathrm{Mat}_{m \times (n+1)}\). Let
\({\varvec{w}} \in \mathbb W_n\) and
\({\varvec{w}}^+ \in \mathbb W_{n+1}\) be such that
\(w^+_j=w_j\), for each
\(j=1,\ldots ,n\),
\(j \ne k\), and
\(w^+_k + w^+_{n+1} = w_k\). Then
\(\mathcal F_C({\varvec{w}^+}, A^+)=\mathcal F_C({\varvec{w}}, A)\).

Proof

Let
\(W=\text {diag}({\varvec{w}}) \in \text {Mat}_{n \times n}\) and
\(W^+=\text {diag}({\varvec{w}^+}) \in \text {Mat}_{(n+1) \times (n+1)}\). Recalling Definition
4, it is enough to prove that
\(\mathrm{rank}(A^+W^+)=\mathrm{rank}(AW)\) and
\(C(A^+ W^+)=C(AW)\). The first equality is immediate; we prove the second equality by considering the following three cases:
\(w_k^+=w_k\) and
\(w_{n+1}^+=0\);
\(w_k^+=0\) and
\(w_{n+1}^+=w_k\);
\(w_k^+>0\) and
\(w_{n+1}^+>0\). In the first case,
\(w_k^+=w_k\) and
\(w_{n+1}^+=0\), the matrix
\(A^+W^+\) can be expressed as
\(A^+W^+=(AW|{\varvec{0}}_{m \times 1})\), so the invariance by size property of
C yields
\(C(A^+W^+)=C(AW)\). In the second case,
\(w_k^+=0\) and
\(w_{n+1}^+=w_k\), the matrix
\(A^+W^+\) can be expressed as
\(A^+W^+=(AW|{\varvec{0}}_{m \times 1})\varPi \), where
\(\varPi \) is a permutation matrix only exchanging the
kth and
\((n+1)\)th positions. Applying the invariance by columns permutations and by size we obtain
\(C(A^+W^+)=C(AW)\). In the last case,
\(w_k^+>0\) and
\(w_{n+1}^+>0\), with
\(w_k^+ + w_{n+1}^+=w_k\), we let
\(w_{k^+}=b w_k\), with
\(b>0\). The matrix
\(A^+W^+\) can be expressed as
and applying the invariance for size and under one scalar multiplication we obtain
\(C(A^+W^+)=C(A^1w_1,\ldots ,c A^k w_k,\ldots , A^n w_n)=C(AW)\).
\(\square \)

$$\begin{aligned} A^+W^+=(A^1w_1,\ldots ,A^{k-1}w_{k-1}, \alpha A^k w_k,A^{k+1}w_{k+1},\ldots , A^n w_n, A^k w_{n+1}^+), \end{aligned}$$

Proposition 4

(Size monotonicity) Let
C be a function of
\(\mathcal H^{m,n}\) that assumes values in
\([1,+\infty )\) and satisfies properties (ii), (v) of Definition
1. Let
\(A \in \mathrm{Mat}_{m \times n}\) be a nonzero matrix and
\(A^+=(A\,|\,A^{n+1}) \in \mathrm{Mat}_{m \times (n+1)}\) with
\(A^{n+1} \ne A^j\) for each
\(j=1,\ldots ,n\). Let
\({\varvec{w}^+} \in \mathbb W_{n+1}\) be such that
\(\overline{\varvec{w}} = \sum _{j=1}^n w_j >0\) and let
\({\varvec{w}}=\frac{1}{\overline{\varvec{w}}}(w_1,\ldots ,w_n) \in \mathbb W_n\). Then
\(\mathcal F_C({\varvec{w}}^+, A^+) \ge \mathcal F_C({\varvec{w}}, A)\).

Proof

Let
\(W=\text {diag}({\varvec{w}}) \in \text {Mat}_{n \times n}\) and
\(W^+=\text {diag}({\varvec{w}^+}) \in \text {Mat}_{(n+1) \times (n+1)}\). By hypothesis on
\({\varvec{w}}\) and
\({\varvec{w}^+}\), the matrix
\(A^+W^+\) can be expressed as
\(A^+W^+=(\overline{\varvec{w}} AW | w_{n+1}A^{n+1})\); consequently, we have either
\(\mathrm{rank}(A^+W^+) =\mathrm{rank}(AW)+1\) or
\(\mathrm{rank}(A^+W^+) =\mathrm{rank}(AW)\). In the first case,
\(\mathrm{rank}(A^+W^+) = \mathrm{rank}(AW)+1>\mathrm{rank}(AW)\), so Proposition
1 item
4 yields
\(\mathcal F_C({\varvec{w}^+}, A^+)>\mathcal F_C({\varvec{w}}, A)\). In the second case, that is if
\(\mathrm{rank}(A^+W^+)=\mathrm{rank}(AW)\), using the properties of invariance for size and 0-degree homogeneity of
C, it follows that:
therefore
\(\mathcal F_C({\varvec{w}^+}, A^+) = \mathcal F_C({\varvec{w}}, A)\).
\(\square \)

$$\begin{aligned} C(A^+W^+) = C((\overline{\varvec{w}} AW | w_{n+1}A^{n+1})) = C(\overline{\varvec{w}} AW) = C(AW), \end{aligned}$$

Proposition 5

(Translation invariance) Let
C be a function of
\(\mathcal H^{m,n}\) that satisfies property (i) of Definition
1, let
\(A \in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\alpha \in \mathbb R\). If no rows and no columns of
A are equal to
\(\mathbf {1}_{1\times n}\) and
\(\mathbf {1}_{m\times 1}\) respectively, then
\(\mathcal F_C({\varvec{w}}, A+ \alpha )=\mathcal F_C({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

Proof

Let
\(W=\text {diag}({\varvec{w}}) \in \text {Mat}_{n \times n}\) and note that the matrix
\(A+ \alpha \) can be expressed as
\(A+\alpha =A+ \alpha \mathbf {1}_{m\times n}\), with
\(\mathrm{rank}(\alpha \mathbf {1}_{m\times n})=1\) in the nontrivial case
\(\alpha \ne 0\). Consequently
\((A+ \alpha )W = AW+\alpha \mathbf {1}_{m\times n} W\) and, using the hypothesis on
A and the rank-sum inequality, see Horn and Johnson [
15, Section 0.4.5], we obtain
\(\mathrm{rank}((A+\alpha )W)=\mathrm{rank}(AW)\). Further, the property of
C of being invariant under independent translations yields
\(C((A+\alpha )W) = C(AW+\alpha \mathbf {1}_{m\times n}W) = c(AW)\) which, coupled with the rank result and Definition
4, concludes the proof.
\(\square \)

Proposition 6

(Homogeneity) Let
C be a function of
\(\mathcal H^{m,n}\) that satisfies property (v) of Definition
1, let
\(A \in \mathrm{Mat}_{m \times n}\) be a nonzero matrix and
\(\alpha >0\). Then
\(\mathcal F_C({\varvec{w}}, \alpha A) = \mathcal F_C({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

Proof

Let
\(W=\text {diag}({\varvec{w}}) \in \text {Mat}_{n \times n}\). By recalling Definition
4 and exploiting the equality
\(\mathrm{rank}(\alpha AW)=\mathrm{rank}(AW)\) and the degree 0 homogeneity of
C, it immediately follows that
\(\mathcal F_C({\varvec{w}}, \alpha A) = \mathcal F_C({\varvec{w}}, A)\).
\(\square \)

Proposition 7

(Symmetry) Let
C be a function of
\(\mathcal H^{m,n}\) that satisfies property (iii) of Definition
1, et
\(A \in \mathrm{Mat}_{m \times n}\) be nonzero and
\(\varPi \in \mathrm{Mat}_{n \times n}\) be a permutation matrix. Then
\(\mathcal F_C(\varPi {\varvec{w}} , A \varPi ) = \mathcal F_C({\varvec{w}}, A)\) for each
\({\varvec{w}} \in \mathbb W_n\).

Proof

Let
\(W=\text {diag}({\varvec{w}}), W_{\varPi }=\text {diag}(\varPi {\varvec{w}}) \in \text {Mat}_{n \times n}\); we have
\(W_{\varPi }=\varPi ^t W \varPi \). We consider the matrix
\(A \varPi W_{\varPi }=A \varPi \varPi ^t W \varPi = A W \varPi \): since
\(\mathrm{rank}(A W \varPi ) = \mathrm{rank}(AW)\) and, by hypothesis on
C,
\(C(A W \varPi ) = C(AW)\), recalling Definition
4, the result immediately follows.
\(\square \)

## 4 Induced portfolio diversification measures

In this section, starting from four fixed PMCs, the Maximum Variance Inflation Factor (M-VIF), see Belsey et al. [
2], the Power Mean measures
\(\mu _k^1\), see Maggi et al. [
18], the Market Rank Indicator (MRI), see Figini et al. [
12], and the Cumulative Risk Fraction
\(h_k\), see Billio et al. [
3], and using the function
\(\mathcal F\) introduced in Sect.
3, see Definition
4, we explicitly construct original portfolio diversification measures. We prove that
\(\mathcal F_{\text {M-VIF}}\) is a CPDM, whereas
\(\mathcal F_{\mu _k^1}\),
\(\mathcal F_{s_k}\) and
\(\mathcal F_{h_k}\) only partially verify the theoretical requirements of CPDMs. Since, in general, the PMCs are only defined in the case of full-rank matrices, we introduce for each considered PMC a possible generalization that, exploiting the classical Gauss–Jordan elimination method, allows us to treat even the case of rank-deficient matrices. To this end, in the rest of the section, for each nonzero matrix
\(A\in \text {Mat}_{m \times n}\) we denote by
\(r=\mathrm{rank}(A-\overline{A})\) and by
\((A-\overline{A})^P = ((A-\overline{A})^{p_1},\ldots ,(A-\overline{A})^{p_r})\) the matrix obtained applying the Gauss–Jordan elimination method to
\(A - \overline{A}\).

### 4.1 The Variance Inflation Factor

In Maggi et al. [
18], based on the classical econometric measure known as
Variance Inflation Factors (VIFs), see for instance Belsey et al. [
2], it is proved that the maximum VIFs provides a measure of connectedness. In the following definition we recall and extend this notion to be defined for mean-centered variables even in the case of rank deficient matrices (we also refer to Gross [
13] for the definition of the centered VIFs).

Definition 5

(Maximum Variance Inflation Factor—M-VIF) The
Variance Inflation Factors
\(\text {VIF}_j: \{A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\} \,|\, r=\mathrm{rank}(A-\overline{A})>1\} \rightarrow \mathbb R\),
\(j = 1,\ldots ,r\), are defined by
where
\(R_j^2\) is the
coefficient of determination of the linear regression of
\((A-\overline{A})^{p_j}\) with respect to
\(\{(A-\overline{A})^{p_i} \,|\, i=1,\dots ,r, i\ne j\}\). The
Maximum Variance Inflation Factor
\(\text {M-VIF}: \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\} \rightarrow \mathbb R\) is defined by
for each
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\).

$$\begin{aligned} \text {VIF}_j(A) = \text {VIF}_j((A-\overline{A})^P) = \frac{1}{1- R_j^2}, \quad j = 1,2,\ldots ,r, \end{aligned}$$

$$\begin{aligned} \text {M-VIF}(A) = \left\{ \begin{array}{lll} 1 &{}&{} \text {if } r=1\\ \max \{\text {VIF}_1(A), \ldots , \text {VIF}_r(A)\} &{}\qquad &{} \text {if } r>1 \end{array}\right. \end{aligned}$$

The measure M-VIF verifies the following important properties.

Proposition 8

The measure M-VIF assumes values in
\([1,+\infty )\) and satisfies properties (i)-(vi) of Definition
1.

Proof

Let
\(A\in \text {Mat}_{m \times n}\) be a nonzero matrix. In the trivial case of
\(r=1\) then
\(\text {M-VIF}(A)=1\); otherwise, since each coefficient of determination
\(R^2_j \in [0,1]\), it holds
\(\text {VIF}_j(A) \ge 1\) and consequently
\(\text {M-VIF}(A) \in [1,+\infty )\). We prove (
i)-(
vi).
\(\square \)

(i)

We consider the nontrivial case
\(r>1\) and note that the coefficient of determination
\(R_j\) satisfies
\(R_j^2 = 1- \frac{\Vert r_j\Vert ^2}{\sum _{i=1}^r \Vert A^{p_i}-\overline{A^{p_i}}\Vert ^2}\) where, for each
\(i=1,\ldots ,r\),
\(r_j\) is the residual vector of the linear regression of
\(A^{p_j}-\overline{A^{p_j}}\) with respect to
\(\{A^{p_i} - \overline{A^{p_i}}\,|\, i=1,\dots ,r, i\ne j\}\). Then
\(1-R_j^2\) is invariant under independent translation of the columns of
A. In the rest of the proof w.l.o.g. we assume that each
\(\overline{A^j}=0\).

(ii)

We let
\(b \in \text {Mat}_{m \times 1}\) and suppose that
\(\mathrm{rank}(A | b) = \mathrm{rank}(A)=r\). If
\(r=1\) then by definition
\(\text {M-VIF}((A | b)) = \text {M-VIF}(A) =1\). Otherwise, the result follows simply by observing that the lists of pivots obtained by the Gauss-Jordan elimination applied to
A and (
A|
b) are the same.

(iii)

We consider
\(A \in \mathcal M_{m \times n}\) and observe that the property simply follows from axiom
C2 of PMC.

(iv)

We consider the nontrivial case
\(r>1\) and note that the coefficient of determination
\(R_j\) satisfies
\(R_j^2 = 1- \frac{\Vert r_j\Vert ^2}{\Vert A^{p_j}\Vert ^2}\). Therefore
\(\text {VIF}_j(A)\) can be expressed as
Let
\(k \in \{1,\ldots ,n\}\),
\(\alpha >0\) and
\(\widetilde{A}=(A^1,\ldots , \alpha A^k,\ldots ,A^n)\). The list of pivots obtained by the Gauss-Jordan elimination applied to
\(\widetilde{A}\) is
\(P=(p_1,\ldots ,p_r)\). If
\(k \ne p_i\),
\(i=1,\ldots ,r\), then the property is trivially verified. Otherwise, if there exists
\(p_i \in P\) such that
\(p_i=k\), we consider each index
\(j \in \{1,\ldots ,r\}\) and distinguish the two cases:
\(k \ne j\) and
\(k=j\). In the first case, it is easy to verify that the residual vector of the linear regression of
\({\widetilde{A}}^{p_j}=A^{p_j}\) with respect to
\(\{A^{p_1},\ldots , \alpha A^k,\ldots ,A^{p_r}\}\setminus \{A^{p_j}\}\) is
\(r_j\); consequently, relation (
4) yields
\(\text {VIF}_j(\widetilde{A})=\text {VIF}_j(A)\). In the second case, the residual vector of the linear regression of
\({\widetilde{A}}^{p_j}=\alpha A^{p_j}\) with respect to
\(\{A^{p_1},\ldots ,A^{p_r}\} \setminus \{A^{p_j}\}\) is
\(\alpha r_j\); consequently, relation (
4) yields
\(\text {VIF}_j(\widetilde{A})=\frac{\Vert \alpha A^{p_j}\Vert ^2}{\Vert \alpha r_j\Vert ^2} = \text {VIF}_j(A)\). Then, we have
\(\text {M-VIF}(\widetilde{A})=\text {M-VIF}(A)\) so
\(\text {M-VIF}\) is invariant under one scalar multiplication.

$$\begin{aligned} \text {VIF}_j(A) = \frac{\Vert A^{p_j}\Vert ^2}{\Vert r_j\Vert ^2}. \end{aligned}$$

(4)

(v)

By combining item (
iv) with Remark
1 we immediately conclude that
\(\text {M-VIF}\) is homogeneous of degree 0.

(vi)

From item (
iv) it follows that
\(\text {M-VIF}\) satisfies the property
\(\text {M-VIF}(\alpha A W_1+(1-\alpha )AW_2) = \text {M-VIF}(AW_1)=\text {M-VIF}(A W_2)=\text {M-VIF}(A)\) for each
\(\alpha \in [0,1]\),
\(A \in {\mathcal M}_{m \times n}\) and
\({\varvec{w}_1}, {\varvec{w}_2} \in \mathbb W_n\), with
\(W_1=\text {diag}({\varvec{w}_1}), W_2=\text {diag}({\varvec{w}_2}) \in \text {Mat}_{n \times n}\).

Proposition 9

The measure
\(\mathcal F_{\text {M-VIF}}\) satisfies axioms
D1,
D2,
D3,
D4,
D5,
D6,
D7,
D8 and
D9 of Definition
3.

Proof

The proof deeply exploits the properties of
\(\text {M-VIF}\) shown in Proposition
8. In the following we prove that
\(\mathcal F_{\text {M-VIF}}\) satisfies the following axioms.
\(\square \)

D1.

The measure
\(\text {M-VIF}\) is a quasi-convex function assuming values in
\([1,+\infty )\). Then, axiom
D1 follows by applying Proposition
2 to
\(\text {M-VIF}\).

D2.

We let
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\),
\(r=\mathrm{rank}(A)\) and
\(E_j=\text {diag}({\varvec{e}_j})\), for each
\(j=1,\ldots ,r\). Since
\(\mathrm{rank}(AE_j)=1\) and
\(\text {M-VIF}(AE_j) =1\), applying Proposition
1, item 1, we get
\(\mathcal F_{\text {M-VIF}}({\varvec{e}_j}, A)=0\), so that axiom
D2 is proved.

D3.

We let
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\) be such that
\(A^i=A^j\) for each
\(i,j=1,\ldots ,n\). Since
\(\mathrm{rank}(AW)=1\) and
\(\text {M-VIF}(AW) =1\) for each
\({\varvec{w}} \in \mathbb W_n\), with
\(W=\text {diag}({\varvec{w}})\), applying Proposition
1, item 1, we get
\(\mathcal F_{\text {M-VIF}}({\varvec{w}}, A)=0\), so that axiom
D3 is proved.

D4.

The measure
\(\text {M-VIF}\) assumes values in
\([1,+\infty )\), therefore axiom
D4 follows by applying Proposition
1, item 5, to
\(\text {M-VIF}\).

D5.

D6.

D7.

D8.

### 4.2 The Power Mean measures \(\mu _k^1\)

The Power Mean measures, see Maggi et al. [
18], are a family of proper measures of connectedness defined as the ratio between the greatest singular value of the returns and a specified power mean of its smallest singular values. In the following definition we recall this notion in the special case of arithmetic mean, and extend it to be defined for mean-centered variables even in the case of rank-deficient matrices.

Definition 6

Let
\(A\in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\sigma _j((A- \overline{A})^P)\),
\(j=1,\ldots ,r\), be the singular values of
\((A- \overline{A})^P\). For each
\(k \in \{1,\ldots ,r\}\) the
Power Mean measure
\(\mu _k^1(A): \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\} \rightarrow \mathbb R\) is defined by:
for each
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\), where
\(M_1\) denotes the arithmetic mean.

$$\begin{aligned} \mu _k^1(A) = \frac{\sigma _1((A-\overline{A})^P)}{M_1(\sigma _{r-k+1}((A-\overline{A})^P), \ldots , \sigma _{r}((A-\overline{A})^P))} \end{aligned}$$

Proposition 10

The measure
\(\mu _k^1\) assumes values in
\([1,+\infty )\) and satisfies properties (i), (ii), (iii), (v), (vi) of Definition
1.

Proof

Let
\(A\in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\sigma _j((A- \overline{A})^P)\) be the singular values of
\((A- \overline{A})^P\). Using the internal property of the arithmetic mean, we get
which yields
\(\mu _k^1(A)\ge 1\), for each
\(k=1,\ldots ,r\). We prove properties (
i), (
ii), (
iii), (
v), (
vi).
\(\square \)

$$\begin{aligned} M_1(\sigma _{r-k+1}((A-\overline{A})^P), \ldots , \sigma _{r}((A-\overline{A})^P))\le & {} \sigma _{r-k+1}((A-\overline{A})^P)\\\le & {} \sigma _1((A-\overline{A})^P), \end{aligned}$$

(i)

We consider the case that
A has no rows and no columns equal to
\(\mathbf {1}_{1\times n}\) and
\(\mathbf {1}_{m\times 1}\) respectively and let
\(B=(b_{ij}) \in \text {Mat}_{m \times n}\) such that
\(b_{ij}=\beta _j \in \mathbb R\) for each
\(i=1,\ldots ,m\) and
\(j=1,\ldots ,n\). It is straightforward to verify that the mean of
\((A+B)^j\) is
\(\overline{A}^j+\beta _j\) so that, if we denote by
\(\overline{A+B}\) the matrix of the column means of
\(A+B\), we have
\((A+B) - \overline{A+B}= A - \overline{A}\), therefore the property is verified. In the sequel w.l.o.g. we let each
\(\overline{A^j}=0\).

(ii)

By hypothesis
\(\mathrm{rank}(A| b) = \mathrm{rank}(A)=r\), where
\(b \in \text {Mat}_{m \times 1}\); since the Gauss-Jordan elimination of
A and (
A|
b) have the same pivots the result follows.

(iii)

The property is a consequence of axiom
C2 of PMC.

(v)

The property follows from the same property on the measure of connectedness
\(\mu _k^1\), see Maggi et al. [
18].

(vi)

We consider
\(A, B \in \mathcal M_{m \times n}\). A result of convex analysis, see for instance Qi and Womersley [
21], states that the largest singular value and the sum of the
k smallest singular values, viewed as matrix functions, are convex and concave functions respectively. Thus, for each
\(\alpha \in [0,1]\), we get:
It is straightforward to verify that
\(\max _{\alpha \in [0,1]} F(\alpha ) = \max \{ \mu _k^1(A), \mu _k^1(B)\}\), which yields the quasi-convexity property
\(\mu _k^1(\alpha A +(1 - \alpha ) B) \le \max \{ \mu _k^1(A), \mu _k^1(B)\}\).

$$\begin{aligned} \mu _k^1(\alpha A +(1 - \alpha ) B)= & {} \frac{k \sigma _1(\alpha A +(1 - \alpha ) B)}{\sum _{j=r-k+1}^r \sigma _{j}(\alpha A + (1- \alpha )B) }\\\le & {} \frac{k(\alpha \sigma _1(A) + (1- \alpha ) \sigma _1(B))}{\alpha \sum _{j=r-k+1}^r \sigma _{j}(A) +(1- \alpha ) \sum _{j=r-k+1}^k \sigma _{j}(B)}\\= & {} F(\alpha ). \end{aligned}$$

Proposition 11

The measure
\(\mathcal F_{\mu _k^1}\) satisfies axioms
D1,
D2,
D3,
D4,
D6,
D7,
D8 and
D9 of Definition
3.

Proof

It is worthwhile to note that the the special case
\(k=1\) yields the matrix 2-norm condition number
\(\mathcal K\), that is
\(\mu _1^1 \equiv \mathcal K\) (and the same situation occurs with the Market Rank Indicator, see Section
4.3). In this case, the associated portfolio diversification measure is
\(\mathcal F_{\mathcal K}({\varvec{w}},A)=1-(\mathrm{rank}(AW)+\mathcal K(AW)^{-1}-1)^{-1}\), which supports the idea that portfolios with highly dependent assets provides less diversification opportunities.

### 4.3 The Market Rank Indicator

The notion of Market Rank Indicator (MRI), see Figini et al. [
12], is defined as a ratio of some of the eigenvalues of a given matrix and it is useful to detect the collinearity between the columns of the input matrix. In the following definition we recall the MRI and extend it to be defined for mean-centered variables even in the case of rank-deficient matrices.

Definition 7

Let
\(A\in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\sigma _j((A- \overline{A})^P)\),
\(j=1,\ldots ,r\), be the singular values of
\((A- \overline{A})^P\). For each
\(k \in \{1,\ldots ,r\}\) the
Market Rank Indicator (MRI)
\(s_k: \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\} \rightarrow \mathbb R\) is defined by:
for each
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\).

$$\begin{aligned} s_k(A) = \frac{\sigma _1((A-\overline{A})^P)}{\left( \prod _{j=k+1}^r \sigma _j((A-\overline{A})^P) \right) ^{\frac{1}{k}}} \end{aligned}$$

Proposition 12

The measure
\(s_k\) assumes values in
\([1,+\infty )\) and satisfies properties (i), (ii), (iii), (v) of Definition
1.

Proof

Let
\(A\in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\sigma _j((A- \overline{A})^P)\) be the singular values of
\((A- \overline{A})^P\). Using the internal property of the geometric mean, we get
which yields
\(s_k(A)\ge 1\), for each
\(k=1,\ldots ,r\). The proof of properties (
i), (
ii), (
iii), (
v) is analogous to the case of
\(\mu _k^1\) (see proof of Proposition
10) and therefore is omitted.
\(\square \)

$$\begin{aligned} \left( \prod _{j=r-k+1}^r \sigma _j((A-\overline{A})^P) \right) ^{\frac{1}{k}} \le \sigma _{r-k+1}((A-\overline{A})^P) \le \sigma _1((A-\overline{A})^P) \end{aligned}$$

Proposition 13

### 4.4 The Cumulative Risk Fraction

The notion of Cumulative Risk Fraction, see Billio et al. [
3], is defined as the portion of the variability of the returns explained by the first principal components. In Maggi et al. [
18] it is proved that the Cumulative Risk Fraction provides a measure of connectedness. In the following definition we recall this notion, rescale it to assume values in the range
\([1,+\infty )\) and extend it to be defined even in the case of rank deficient matrices.

Definition 8

Let
\(A \in \text {Mat}_{m \times n}\) be a nonzero matrix and
\(\sigma _j((A- \overline{A})^P)\),
\(j=1,\ldots ,r\), be the singular values of
\((A- \overline{A})^P\). For each
\(k \in \{1,\ldots ,r\}\) the function
\(h_k: \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\} \rightarrow \mathbb R\) is defined by:
for each
\(A \in \text {Mat}_{m \times n} \setminus \{{\varvec{0}}_{m \times n}\}\).

$$\begin{aligned} h_k(A) = \frac{\sum _{j=1}^r \sigma _j^2((A-\overline{A})^P)}{\sum _{j=1}^k \sigma _j^2((A-\overline{A})^P)}. \end{aligned}$$

It is easy to observe that, in the case of full-rank matrices, Definition
8 coincides with the inverse of the Cumulative Risk Fraction as given in Billio et al. [
3].

Proposition 14

The measure
\(h_k\) assumes values in
\([1,+\infty )\) and satisfies properties (i), (ii), (iii), (v) of Definition
1.

Proof

Using the definition, it is immediate to verify that
\(h_k(A)\ge 1\), for each
\(k=1,\ldots ,r\). Further, since the Cumulative Risk Fraction is homogeneous of degree 0, see Maggi et al. [
18], the same property holds for the measure
\(h_k\). For the proof of properties (
i), (
ii), (
iii), (
v) we refer to the analogous case of
\(\mu _k^1\) (see proof of Proposition
10).
\(\square \)

Proposition 15

## 5 Conclusions

In this paper we compared the PMCs and the CPDMs starting from their respective axiomatic characterizations. The generality of the proposed approach permits to discuss the properties a PMC needs to verify in order to belong to the class of CPDMs, once the transformation defined by the function
\(\mathcal F\) is applied. Such transformation function
\(\mathcal F\) supports the intuition described in the introduction that a strong relation links the concepts of connectedness and diversification; in particular, given the number of assets in a portfolio, an increase in the connectedness reflects a reduction of the diversification opportunities. The central result of the paper is the definition of the induced CPDM starting from a PMC that verifies some required additional properties. In practice, we showed that the VIF induces a CPDM, while other popular PMCs, as the Cumulative Risk Fraction, the Market Rank Indicator and the Power Mean measures, including the special case of the condition number, only partially verify the requirements to define an induced CPDM. While in the present paper, for the sake of simplicity, we focused on the transformation from connectedness to diversification, in our future research we plan to investigate the opposite transition, from diversification to connectedness.

## Conflict of interest

The authors declare that they have no conflict of interest.

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